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UNIVERSITY OF CALIFORNIA EVOLUTIONARY FORCES AT WORK IN THE HUMAN A dissertation submitted in partial satisfaction of the requirements for the degree of DOCTOR OF PHILOSOPHY The Dissertation of Sol Katzmanis approved: Professor David Haussler, Chair Professor Kevin Karplus Professor Nader Pourmand Professor Alan Zahler Tyrus MillerVice Provost and Dean of Graduate Studies Table of Contents Population Genetics Concepts . . . . . . . . . . . .
The Ultraconserved Elements . . . . . . . . . . . .
The Human Accelerated Regions . . . . . . . . . . .
Ultraconserved Elements are Ultraselected Definition of Selection Coefficient . . . . . . . . . . .
Definition of UX, UC, UF regions . . . . . . . . . . .
Sample Populations Selection of Primers Processing of Chromatograms . . . . . . . . . . . .
Validation of Singletons . . . . . . . . . . . . . .
Tuning the Polymorphism Rank Parameter . . . . . . . .
UC vs. UF Quality Comparison . . . . . . . . . . . .
2.10 Sequence Analysis 2.11 Seattle SNPs Comparative Analysis 2.12 Hierarchical Bayesian Model [AK] 2.13 MCMC Implementation and Convergence [AK] . . . . . . .
2.14 Maximum Likelihood Estimates [AK] . . . . . . . . . .
2.15 Effect of Linkage Disequilibrium 2.16 Ascertainment Effects [AK] . . . . . . . . . . . . .
2.17 Correcting for Ascertainment Bias [AK] . . . . . . . . .
Evolution of Human Accelerated Regions is GC-Biased Results of HAR Neighborhood Analysis . . . . . . . . .
Weak-to-Strong Mutations are Being Swept to Higher DerivedAllele Frequencies Weak-to-Strong Mutations are More Likely to Have Become FixedDifferences The Scale of Fixation Bias towards Weak-to-Strong MutationsVaries . . . . . . . . . . . . . . . . .
No Significant Evidence for Selective Sweeps Methods for HAR Neighborhood Analysis . . . . . . . . .
Sample Data Genomic DNA Selection . . . . . . . .
Target Regions and Nimblegen Enrichment Array Design . .
SOLiD Barcoded Library Preparation . . . . . . . .
Sequence Mapping, Filtering, and Genotyping . . . . . .
Derived Allele Frequencies and SweepFinder . . . . . .
MWU and MK tests on Harseq and Ctlreg Regions . . . .
MWU and MK Tests on Seattle SNPs Regions and Simulations .
A Supplementary Tables Mutations Subject to Neutral Drift . . . . . . . . . . .
Mutations Subject to Positive and Negative Selection . . . . . .
Genetic Hitchhiking Ultraconserved elements are under stronger selection than Protein CodingRegions . . . . . . . . . . . . . . . . . .
Derived Allele Frequency Spectra for UC, UF, Introns, Nonsynonymous Estimates of Selection Coefficients for UC, UF, Introns, NonSynonymous Correction of Ascertainment Bias of Ultraconserved Elements in Esti-mates of Selection Coefficient . . . . . . . . . . . .
Distributions of quality scores for UC and UF regions Boxplots of quality scores for UC and UF regions . . . . . . .
Posterior Distributions of the mean selection coefficient MCMC output from one dataset . . . . . . . . . . .
Convergence plots for MCMC simulations . . . . . . . . .
2.10 Selection Coefficient Estimates without Linkage Disequilibrium . . .
2.11 Effect of Ascertainment Bias of Ultraconserved Elements on Tajima's D and Estimates of Selection Coefficient Frequency offset of W2S vs. S2W mutations . . . . . . . .
Population Genetic Statistics in harseq regions and Seattle SNPs genes .
SweepFinder Composite Likelihood Ratio (CLR) in genomic context .
HAR Region Mapping Statistics by Sample . . . . . . . .
Histogram of Hardy-Weinberg Equilibrium Test . . . . . . .
Accuracy of MWU Test p-values . . . . . . . . . . .
Accuracy of MK Test p-values . . . . . . . . . . . .
Segregating Sites Counts for 332 UX Fully Sequenced Elements . . .
Segregating Sites Counts for 315 UX Elements with Chimp and RhesusAlignments . . . . . . . . . . . . . . . . .
Population Genetic Summary Statistics Estimates of the selection coefficient . . . . . . . . . .
Estimates of the selection coefficient using Bayesian and Maximum Like-lihood methods . . . . . . . . . . . . . . . .
Ultraconserved Element Ascertainment Bias Correction in Estimates ofthe selection coefficient . . . . . . . . . . . . . .
MWU Test Significant Regions . . . . . . . . . . . .
MK Test Significant Regions HAR Region Mapping Statistics A.3 Seattle SNPs Gene Region MWU and MK Test Results . . . . .
Evolutionary Forces at Work in the Human Genome Conservation of genomic sequences through evolutionary history provides a powerful tool to guide biological investigations towards functionally important regions.
In this work I have investigated two sets of such conserved sequences. The first set are the Ultraconserved Elements (UCEs). These are stretches of at least 200 basepairs (bp) of DNA in the human genome that match identically with corresponding regions in the mouse and rat genomes. Most UCEs are noncoding and have been evolutionarily conserved since mammal and bird ancestors diverged over 300 million years ago. The second set are the Human Accelerated Regions (HARs). These are elements ranging in size from 100–400bp that were generally conserved throughout vertebrate evolution, but that show an unexpected number of human-specific changes. For both analyses I used human polymorphism data. For the UCEs, resequencing of genomic DNA from 72 diploid human samples was performed by the sequencing center at Washington Univer- sity using conventional capillary electrophoresis (CE) methods. I aggregated the small number of polymorphic sites found in more than 300 UCEs and analyzed the result- ing derived allele frequency (DAF) spectrum to show that the UCEs as a whole are under negative (purifying) selection that is much stronger than that in protein coding genes. In contrast, my analysis of the top 49 HARs used the latest generation of high throughput sequencing technology. I implemented a technique to enrich the genomic DNA from 11 human samples (i.e. 22 chromosomal samples per locus) for 40kb neigh- borhoods of these 49 HARs. After obtaining short read sequences for this enriched DNA from the sequencing center at UC Santa Cruz, I mapped these reads to the reference human genome, used the mapped sequences to call polymorphic genotypes, and con- structed the DAF spectrum for each HAR. My analysis of these spectra showed only weak evidence for selective forces, which was not significant after correction for multiple hypothesis testing. However, I performed other analyses considering the pattern of nu- cleotide substitutions from the ancestral to the derived alleles. I found that in addition to an historical bias favoring the conversion of weak (A or T) alleles into strong (G or C) alleles there is also strong evidence in the DAF spectra of many of these 40kb regions for ongoing weak-to-strong (W2S) fixation bias. Together, these results do not rule out functional roles for the observed changes in the HARs — indeed there is good evidence that the first two HARs are functional elements in humans — but they suggest that a fixation process (such as biased gene conversion) that is biased at the nucleotide level but is otherwise selectively neutral, could be an important evolutionary force at play in them, both historically and at present.
I dedicate this dissertation to my wife Lisa, whose kind words of encouragement are invaluable to me.
I want to thank my committee for helping me to achieve this degree.
I thank Kevin Karplus for encouraging me to get started in bioinformatics research. I thank Al Zahler and Melissa Jurica for my initial training in wetlab pro- cedures. I thank my adviser David Haussler for providing me the opportunity and resources to pursue genomic research. The depth and breadth of his scientific expertise are awe inspiring. I especially thank Sofie Salama for mentoring me over several years through numerous research paths, some yielding fruit and some not. Her unwavering support and unfailingly cheerful demeanor, as well as her incredible intellect have been I thank my collaborators Andy Kern and Katie Pollard for freely sharing their expertise. I thank all the members of the UC Santa Cruz Genome Browser staff and especially Mark Diekhans, Hiram Clawson, and Kate Rosenbloom for guidance in re- solving various software issues. I thank all of the teachers whose courses I have had the privilege of taking during my graduate studies at UC Santa Cruz.
I thank fellow wetlab members Jason Underwood, Bryan King, Bob Sellers and Dave Greenberg for help with lab protocols and procedures. I thank Nader Pourmand and the members of his Genome Sequencing lab, especially Eveline Farias-Hesson. I thank my fellow graduate students including Robert Baertsch, Daryl Thomas, Craig Lowe, and Courtney Onodera for freely sharing their knowledge as we all progressed.
Understanding the forces that have shaped the evolution of the human genome is one of the most exciting problems in modern genomics. Two approaches to this problem are focused on identification and characterization of those genomic regions that have evolved the slowest and fastest along the human lineage [7, 83, 60, 62, 9].
The slowest evolving regions may contain elements that cannot be disturbed without disrupting essential function. The fastest evolving regions may harbor elements whose function is unique to our species' lineage. To eliminate non-functional regions, both of these complementary approaches begin with a search for regions that are conserved throughout mammalian history or longer. In my work I have analyzed one set of each type, employing various tools derived from the theory of population genetics. In the following sections I first provide some background material describing the concepts underlying such tools and then describe their application to the two sets of genomic regions that I studied.
Population Genetics Concepts In this section I give a brief introduction to several concepts from the the- oretical science of population genetics that are helpful in understanding the analyses employed in my work on the two sets of genomic regions described in this dissertation.
For a more thorough, but still very accessible treatment, I suggest the excellent book by Gillespie [28]. For an application of these principles and much more information about human evolution I recommend the book by Jobling, Hurles, and Tyler-Smith [33].
A good starting point in population genetics is the Wright-Fisher model of a population, named in honor of two pioneers of the field, Sewall Wright and R. A. Fisher.
In this model, the population size remains constant between successive generations.
From one generation to the next, considering a single genomic locus (e.g. one nucleotide position on a chromosome), a random set of the copies in the current generation is chosen (with replacement) to propagate to the next generation. To a certain extent, this model represents a randomly mating population, which is not at all realistic for the human species as a whole or even human subpopulations. Nevertheless, it is very useful when used in connection with the concept of an effective population size, abbreviated Ne.
To grasp this concept first consider a bi-allelic locus (i.e. a locus at which there are only 2 possible variants (alleles), such as a nucleotide position that is either A or G in a population). Suppose the fraction of the two alleles are p and q, where p + q = 1. In a Wright-Fisher population of size Ne, one can calculate the variance in the value of p after one generation as By using a suitable value of Ne one can encapsulate much of the deviation from the model that is inherent in a real population, such as the fact that mating is far from random, or that some individuals have many offspring and some have none, or even that the concept of generation defined in the model does not apply to a real population. The relevant constraint is to choose a value of Ne for the real population for which Equation 1.1 is valid, so that a Wright-Fisher model can be used. As will be discussed below, the effective population size relates (under the model) several observable quantities at the population level, such as diversity, to those that may be estimated at the molecular level, such as mutation rate per generation. In fact, using those two stated quantities, various estimates of Ne for the human population have been derived (e.g. see Table 6.1 in the book by Jobling, Hurles, and Tyler-Smith [33]), which are all generally in the range of 10,000 — quite a bit smaller than the actual human population of nearly 7 billion.
If in addition to the random mating aspect of the Wright-Fisher model, one adds the (unrealistic) assumptions of an infinite population size with no mutations or selection (i.e. no evolution), one can show that polymorphic loci in the model almost immediately reach Hardy-Weinberg Equilibrium (HWE). This phrase denotes that the genotypes at a locus (i.e. the 3 possible diploid combinations of the two alleles) have a binomial distribution. That is, using the p and q notation from above, the fraction of heterozygotes in the population is 2pq, and the fractions of the two homozygotes are p2 and q2. Despite its dependence on unrealistic absolute assumptions, large deviations from HWE are rare in cases where the assumptions are even approximately true. There- fore it is advisable to test for HWE when discovering novel genotypes in a set of samples as I have done in this work (see Figure 3.5). One further consequence of HWE is that rare alleles are found almost exclusively in heterozygote (as opposed to homozygote) individuals because 2pq is much greater than p2 when p is very small.
In order to describe the relationship between allele frequencies (p1, q1) and (p2, q2) at two neighboring loci, the somewhat convoluted phrase Linkage Disequilib- rium (LD) is used. In this context "equilibrium" refers to the theoretical case where knowledge of p1 provides absolutely no information about p2 and vice-versa. By defini- tion, in the presence of LD this is no longer true. Although it has several mathematical formulations, at heart LD is a measure of the correlation between the two loci. It arises naturally enough because of the physical connection between them on the DNA strand, which is only broken if a recombination event occurs during meiosis that joins the pater- nal chromosome's allele at one locus to the maternal chromosome's allele at the other.
As such, greater physical distance between loci on the DNA strand, or any other factor that increases the chance of recombination between them leads to lower LD, whereas higher observed LD can be interpreted as arising from a lower rate of recombination between them.
Another central concept that I make extensive use of in this work is that of the derived allele frequency (DAF) spectrum. In terms of a population, this can be understood as the distribution of allele frequencies (denoted p above) for a set of polymorphic loci. But crucially, the alleles must be polarized into the ancestral versus derived versions and p is taken as the fraction of derived alleles in the population.
In the current genomic era this polarization can usually be done for loci in the human genome by comparing the homologous regions in several primate genomes. Although the population genetic theory is applied to the population DAF, in practice the observable quantities consist of the fraction of ancestral alleles at a set of loci in the set of samples studied. In my work, I have restricted my attention to single nucleotide polymorphism (SNPs) obtained from resequencing DNA from sets of samples.
Furthermore, only the sites which are observed to be polymorphic among the samples contribute to the estimated DAF spectrum, which can be visualized as a histogram of the calculated frequencies, as in Figure 2.2. The bin size used on the X-axis of these histograms is often taken to be the normalized minimal value — a single chromosomal sample from the diploid individuals resequenced. Another bit of nomenclature is to refer to the sites that are polymorphic in the sample as "segregating" sites and therefore an often used synonym for the DAF spectrum is the site frequency spectrum (SFS).
Given a Wright-Fisher model, the next step is to consider mutations entering the (constant size) population at various sites on the genome or in a genomic region.
A common simplifying assumption is that there are infinitely many such sites. This has the effect of simplifying some of the mathematical formulae, and also implies that once a mutation occurs at a site, there is zero probability of a reverting mutation at the same site. If the mutations that enter have no effect on the random selection described above for propagation of alleles from one generation to the next, then we have arrived at the so-called Standard Neutral Model (SNM). On the other hand some mutations can either reduce or enhance the reproductive fitness of an individual, leading to a layer of selection (negative or positive) that is added to the model and affects the shape of the DAF spectrum.
To illustrate these concepts some simplified examples can be considered. In the first example (Figure 1.1) the region under consideration is not subject to selection, so that all mutations are selectively neutral. The shape of the DAF spectrum is determined by the stochastic phenomenon of neutral drift wherein the allele frequency of a mutation during a given generation is determined by its position in the (random) geneology.
Since mutations are continually entering the population at the lowest possible frequency (namely on one chromosome of one individual), the DAF spectrum of a neutral region is strongly skewed toward the low end.
On the other hand, if a region is strongly constrained, such that its bases are subject to negative (a.k.a. purifying) selection (Figure 1.2 upper panel) then the deleterious effect on fitness of most mutations means that they do not spread to higher derived allele frequencies. The DAF spectrum will be even more highly skewed to low frequencies than that for a neutrally evolving region. Very few polymorphic positions will have derived allele frequencies above 0.5 Now consider the impact of a beneficial mutation (Figure 1.2 lower panel).
Such a single mutation sweeping towards fixation at one site, by itself has little impact Neutral mutation can drift to oblivion
Neutral mutation can drift to fixation
Figure 1.1: Mutations Subject to Neutral Drift. The action of neutral drift on allele frequencies. A selectively neutral mutation can either drift to oblivion (upper panel) or to fixation (lower panel) in a population depending on where in the geneology it happens to occur. Numbers at the right edge indicate the count of mutated alleles in the population at each generation moving from top to bottom.
on the overall spectrum. Of course, if only beneficial mutations enter the population the spectrum would be skewed towards higher frequencies.
However, even a single beneficial mutation can cause the spectrum to change shape due to the phenomenon of genetic hitchhiking (Figure 1.3). Alleles adjacent to the beneficial mutation on the same chromosome benefit from its reproductive advantage and thus also sweep towards fixation. A neighboring derived allele has its DAF rise while a neighboring ancestral allele has its DAF decrease. The net effect is to increase the skew at both ends of the DAF spectrum. Since the low end is already skewed by either neutral or negative selection, the signature of positive selective is most visible as an increase in the high end. Beyond this simple change in spectrum shape there is also a characteristic spatial pattern to the frequencies at sites along the chromosome in the neighborhood of the beneficial derived allele, which arises due to linkage disequilibrium as described above.
This spatial pattern can be exploited to test for evidence of such a selective sweep.
After the sweep has completed, new mutations subject to neutral drift or even negative selection eventually degrade the signal while recombination both during and after the sweep also breaks down the LD among the sites.
Using the observed SFS one can use the population genetic models to estimate whether a region of interest appears to have been under selection. To quantify the strength of selection, one must first choose a model of reproductive fitness for a diploid genome that can contain zero, one, or two copies of a derived allele. A simple choice, and the one that I used in the work described below, is a straightforward additive model that assigns the relative reproductive fitness values 1 (AA homozygote), 1 + s deleterious mutations do not spread
advantageous mutation drives to fixation
Figure 1.2: Mutations Subject to Positive and Negative Selection. The action of selection on allele frequencies. Deleterious mutations (upper panel) reduce reproductive fitness and do not spread to high allele frequencies. Advantageous mutations (lower panel) enhance reproductive fitness and can rapidly spread to fixation in the population.
No recombination: all hitchhiking alleles fix too With recombination: Figure 1.3: Genetic Hitchhiking. A beneficial mutation enters (at 0% allele frequency) the population on a specific chromosome and sweeps to fixation (100% allele frequency). If there were no recombination (upper panel), then all of its neighboring (on the same chromosome) alleles would also sweep, driving the derived allele frequencies (DAF) to either 0% (for neighboring ancestral alleles, marked "A") or 100% (for neighboring derived alleles, marked "D"). In the presence of recombination (lower panel) the effect is mitigated, but the allele frequencies are still pushed towards the two extremes.
(AD heterozygote), 1 + 2s (DD homozygote) to the three possible combinations of the ancestral (A) and derived (D) alleles in a diploid individual. The quantity s is called the fitness parameter. It has been shown [24, 84] that the DAF spectrum is related to the fitness parameter via the effective population size in terms of the selection coefficient 1 − e−α(1−p) Note that Equation 1.2 applies to the entire population and that further refinements are necessary when doing calculations on segregating sites from samples (see Section 2.12 and Equation 2.3). Since the shape of the DAF spectrum is directly related to α rather than to s, my analysis is aimed at estimating the value of the former. It is noteworthy, however that the strong negative selection that I found in the ultraconserved elements corresponds to a value for α of about negative 5. Using the estimate of 10,000 for the human Ne this corresponds to s = 0.00025. The heterozygote having a deleterious derived allele is only at a 0.025% fitness disadvantage! Put another way, that individual has a 99.975% chance of reproducing compared to anyone else.
Other population genetic parameters also involve Ne. Among these is θ = 4Neu where u is the rate of mutation at the molecular level. The quantity θ arises in several contexts at the population level. In particular it relates the mutation rate to the average heterozygosity in a population that is in equilibrium. Here heterozygosity is defined as the probability that two alleles chosen at random from the population are not the same: From the observed segregating sites in a set of samples, several estimators of θ can be calculated, which are denoted θπ, θW , and θH . Of these, θW depends only on the count of segregating sites in the sample, while θπ derives directly from an estimate of heterozygosity involving the terms 2piqi at each segregating site i in the sample. Note that the latter does not require identification of the derived versus ancestral allele. As such it is a function of the folded SFS. That is, a site with DAF 0.2 is treated the same as a site with DAF 0.8. By contrast, θH is composed from terms q2 where q the derived allele frequency, so that it depends on the unfolded SFS.
In a neutrally evolving region, all of these estimators of θ have the same ex- pected value. By looking for differences between them, various calculated statistics are used to detect deviations from neutrality. Tajima's D [75] is based on the difference between θπ and θW . As such it is a function of the folded SFS and has difficulty distin- guishing between selection and various effects of demographic history of a population, such as bottlenecks or rapid expansion in population size. Because it gained wide cur- rency in the era before we could relatively easily calculate the unfolded SFS, I report it in this work. By contrast, Fay and Wu's H [23] is based on the difference between θπ and θH . Negative values are directly related to a skew towards the high end of the SFS, representative of positive selection as discussed above.
The Ultraconserved Elements The ultraconserved elements (UCEs) in the human genome [7] were originally defined as stretches of at least 200 base-pairs of DNA with 100% identity to ortholo- gous regions in the mouse and rat genomes. Most are non protein-coding regions that are unique to vertebrates, and in fact have undergone little or no evolutionary change since mammal and bird ancestors diverged about 300 million years ago. Large scale transgenic assays in a mouse model suggest that many function as distal enhancers for neighboring developmental genes [56]. However, the reason for their extreme conserva- tion remains a mystery. They could just be unusually large patches of sites under weak but still detectable levels of negative selection, as has been found in some types of con- served non-coding regions [37, 42], or they could merely be mutational cold spots. If the selection is too weak, then it may actually have been ineffective in humans because of our much smaller effective population size relative to the rodents [37, 42]. In my work, I measure the derived (new) allele frequency spectrum for the segregating human poly- morphisms in the ultraconserved regions and show that it is significantly shifted toward rare derived alleles, indicating strong negative selection. Estimating the distribution of selection coefficients at these sites, I find them to be considerably more negative than even those at amino acid-changing (nonsynonymous) sites, indicating stronger selection in ultraconserved noncoding regions than in coding regions.
The signature of negative selection is that any introduced mutations are un- likely to spread to a high proportion of the population. This causes the derived allele frequency (DAF) spectrum to be skewed towards low values. I analyzed genomic DNA sequences in 72 individuals (a mixture of European Americans and African Americans) spanning 315 of the UCEs, and found 134 segregating sites. I compared the DAFs for these sites with those in 314 segregating nonsynonymous sites in 211 genes obtained from 47 individuals of similar background available from the SeattleSNPs consortium The Human Accelerated Regions In contrast to the emphasis on negative selection in the UCEs, several groups have searched for positive selection along the human lineage by focusing on those pre- viously slowly evolving regions of the genome that have evolved most quickly along the human lineage [59, 62, 9]. These regions, such as those in the set of Human Accelerated Regions (HARs) [59], may include some of the genetic changes that make our species biologically unique. Indeed, biological characterization of the topmost elements on this list of candidates has proven fruitful: HAR1 is part of a novel RNA gene (HAR1F) that is expressed during neocortical development [60]; HAR2 (or HACNS1) is a conserved non-coding sequence that has been shown to function as an enhancer in the developing limb bud with the human-specific sequence enhancing expression in the presumptive anterior wrist and proximal thumb [63].
Since the HARs were identified based on an excess of fixed differences between the human reference genome and sequences that are highly conserved among chimp, mouse and rat, such differences could have arisen at any time within the ∼5 million years that have elapsed since our common ancestor with the chimpanzee. As such it is important to recognize that even if such differences resulted from positive selection for advantageous mutations, they may have occurred so long ago that we have little power to find evidence for such selection using only the present day sequences available to us.
Furthermore, as previously noted [59], positive selection might not be the sole explanation for the rapid evolution that is evident in the HARs. Biased gene conversion (BGC) may also hasten the fixation of mutations in a local manner independent of any fitness benefits [26, 19]. BGC arises as a byproduct of recombination between homologous chromosomal regions. In this process DNA double stranded breaks are repaired and the alleles from one chromosome are copied to the other, with a bias for conversion of A or T (weak hydrogen bonding) alleles to G or C (strong hydrogen bonding) alleles [74, 45, 47, 18]. A neutral locus can thus mimic the rapid evolution of loci under positive selection [26, 19], and furthermore, BGC may in fact drive fixation of deleterious alleles [27], the precise opposite of a positive, adaptive evolutionary effect.
As is the case for negative selection, one of the most powerful tools for identify- ing those regions that have been subjected to directional selection comes from examining the DAF spectrum at sites segregating within a species. For example, analysis of this distribution, also known as the site frequency spectrum (SFS), allows for the identifica- tion of loci that have been involved in selective sweeps in the last few hundred thousand years. Analysis of the SFS has been used to identify targets of natural selection that may be responsible for genetic traits that are uniquely human, such as language [20] or cognition [66].
In the current work I investigate the top 49 HARs. But rather than restricting attention to the core elements, which are 100–400bp in length, I consider the poly- morphism in a set of 22 chromosomal human samples in a 40kb neighborhood of each of these HAR elements, with an eye to capturing perturbations in the SFS at linked sites, and/or regionally biased patterns of allele fixation. My samples for this analysis are drawn from a single population, the Yoruba from Ibidan, Nigeria in order to avoid confounding issues of population admixture as well as to take advantage of a greater degree of variation in this population. I use an adaptation of several techniques previ- ously developed [30, 5, 61, 53] to enrich genomic DNA from the sample individuals for the target genomic neighborhoods. The enriched DNA is then subject to high through- put sequencing followed by genome-wide mapping of many overlapping sequences to determine genotypes at sites in the target regions, and hence derive the site frequency With these spectra in hand, it is possible to test for the hallmarks of BGC. I employed an approach that compares the separate site frequency spectra for the weak-to- strong (i.e. A or T to G or C)(W2S) and strong-to-weak (S2W) mutations to determine if any shift towards high frequency, normally characteristic of a selective sweep, is biased towards one of the two sets of mutations. This signal would indicate an ongoing process in the current human population. Similarly, one can compare the proportion of W2S changes among already fixed substitutions on the human or chimp lineage to that among the still segregating sites. A W2S bias in fixed differences relative to polymorphisms would indicate that the regions have historically been subject to a BGC-like biased On the other hand, the spectra may contain evidence of positive selection.
Various techniques have emerged in recent years to search for signatures of positive selection using population genetic data, but many are based on the phenomenon of genetic hitchhiking [46, 34] in which fixation of beneficial mutations results in a skew in the site frequency spectrum.
One such approach [40] is based on the composite likelihood of allele frequencies wherein the probability of the observed allele frequency at each polymorphic position is calculated based on its distance from a site under putative positive selection. This probability explicitly takes into account the strength of recombination and selection. A variant of this approach has been implemented [52] in the SweepFinder program that I use herein. It has been previously used [82] in a genome-wide search for sweeps at the scale of ∼500kb, since that study's data was restricted to loci with common polymorphisms. The power of that approach is probably limited to finding sweeps not much older than ∼200,000 years but has the attractive property that it is robust to demographic history [82]. Unlike other approaches that have been used [68, 69, 79, 77] it also does not require that the sweep be ongoing or differentially concluded in separate populations. Since I have discovered many novel polymorphisms by resequencing the samples, I use this method to take a more focused look at the 40kb HAR neighborhoods in search of adaptive evolutionary forces.
Ultraconserved Elements are Previous studies have indicated that some types of conserved noncoding regions can exhibit selection coefficients comparable to those of protein coding regions [16].
My analysis described in detail below shows that selection in the vertebrate-specific ultraconserved noncoding regions is in fact much stronger. These data, arguing strongly that ultraconserved elements are currently, as well as historically, strongly constrained functional elements were published in the journal Science [36]. Here I describe the results and in the following sections indicate the methods used to derive them. In this work I collaborated with Andrew Kern who implemented the Bayesian MCMC analysis described below as well as the correction needed to compensate for the bias against diversity that is implicit in the definition of the ultraconserved elements. The sections below taken from the published paper that were largely written by Andrew Kern are marked with "[AK]".
As noted in the Introduction, I analyzed genomic DNA sequences in 72 in- dividuals (a mixture of European Americans and African Americans) spanning 315 of the ultraconserved elements, and found 134 segregating sites. I compared the DAFs for these sites with those in 314 segregating nonsynonymous sites in 211 genes obtained from 47 individuals of similar background available from the SeattleSNPs consortium The DAF spectrum of the nonsynonymous sites is consistent with that observed in other studies, but the spectrum for the ultraconserved sites is qualitatively different (Figure 2.1 upper panel). More than half (55%) of the segregating ultraconserved sites are singleton heterozygotes—present in only one allele in one sample—compared to 41% of the nonsynonymous sites. Furthermore, only 4 out of 134 (3%) of the segregating ultraconserved sites exhibit derived allele frequencies of more than 25%, compared to 41 out of 314 (13%) of the segregating nonsynonymous sites (χ2 p-value 0.002), and only 1 of the 134 ultraconserved sites reach DAF > 50%, whereas 22 of the 314 nonsynonymous sites do (χ2 p-value 0.01).
In addition to the segregating sites in the ultraconserved (UC) regions and the nonsynonymous segregating sites in protein coding genes, I also obtained derived allele frequency (DAF) spectra for segregating sites in the moderately conserved bases immediately flanking (UF) the ultraconserved regions and for segregating sites in introns of the protein coding genes (Section 2.2). In Figure 2.2 I recapitulate the DAF spectra of the ultraconserved and nonsynonymous bases, and also supply the spectra observed 134 segregating Ultraconserved sites
314 segregating Nonsynonymous sites
(55% have DAF count=1)
(41% have DAF count=1)
fraction of segregating sites derived allele frequency (DAF) count (of 144) derived allele frequency (DAF) count (of 94) Nonsynonymous sites (peak at −1.6) posterior probability density Ultraconserved sites (peak at −5.0) mean selection coefficient Figure 2.1: Ultraconserved elements are under stronger selection than ProteinCoding Regions. Upper panels: histograms of the derived allele frequency counts for segregating sites in the indicated categories. In each histogram the first bar, corresponding to singleton heterozygotes (derived allele frequency count = 1) is truncated. The actual fraction of singletons is indicated in the title. Lower panel: the Bayesian posterior distributions for the mean selection coefficient. The x-axis is given in units of α = 2Nes, where Ne is the effective population size and s is the fitness parameter.
for the bases flanking the ultras and for the introns.
UC (134 SNPs; 55% have count=1)
NonSyn (314 SNPs; 41% have count=1)
fraction of segregating sites fraction of segregating sites derived allele count (of 144) derived allele count (of 94) UF (201 SNPs; 41% have count=1)
Intron (385 SNPs; 29% have count=1)
fraction of segregating sites fraction of segregating sites derived allele count (of 144) derived allele count (of 94) Figure 2.2: Derived Allele Frequency Spectra for UC, UF, Introns, Nonsyn-onymous. Histograms of the derived allele frequency counts for the 4 indicated categories. In each histogram the first bar, corresponding to singleton heterozygote SNPs (derived allele count = 1) is truncated. The actual fraction of segregating sites for that bar is shown in the title, along with the total number of segregating sites for the associated category. The spectrum for UC elements has a clear dearth of higher frequency polymorphisms compared to the other categories. EA: European Americans.
AA: African Americans. UC, UF: ultraconserved elements and their flanking regions as defined in text, in which EA+AA pooled samples comprise 72 individuals for a total of 144 chromosomes at each site.
NonSyn,Intron: data from Seattle SNPs for nonsynonymous sites in coding regions of, and for introns of, 211 genes as defined in text, comprising a pooled EA+AA set of 47 individuals for a total of 94 chromosomes at each site.
We applied a Bayesian modeling technique to estimate the distribution of se- lection coefficients from these DAF spectra. The model is hierarchical, allowing each segregating site k to have its own selection coefficient αk = 2Nesk, where Ne is the effective population size and sk the basic fitness parameter of the Wright-Fisher model for site k. We assume the αk are drawn independently from a normal distribution with a different mean µ and standard deviation σ for each type of site (e.g. ultraconserved or nonsynonymous). We estimated posterior distributions for µ from the DAF spectra using Markov Chain Monte Carlo (MCMC) methods. The 95% credible intervals of the two posterior distributions do not overlap at all, and a comparison of these distribu- tions implies that the ultraconserved sites are on average under purifying selection that is three times greater than that acting on nonsynonymous sites (Figure 2.1 lower panel).
In Figure 2.3 the posterior distributions of the mean selection coefficient de- rived from all four spectra (UC, UF, introns, nonsynonymous coding) are shown. These indicate that the bases immediately flanking the ultraconserved regions are under se- lection comparable to that for the nonsynonymous sites. This is much weaker negative selection than those within the ultraconserved regions. As expected, the selection on intronic sites is close to neutral.
Such estimates are subject to ascertainment bias, not only in the selection of segregating sites (a bias I avoid by completely resequencing the entire region), but implicit in the definition of the ultraconserved regions themselves. A region of the genome containing a segregating site with high derived allele frequency is likely to show a difference between the reference human genome and the reference genomes of Ultraconserved sitesUltraconserved flanking sitesNonsynonymous sitesIntronic sites P(Selection Coefficient Data) Selection Coefficient Figure 2.3: Estimates of Selection Coefficients for UC, UF, Introns, NonSyn-onymous. Results of hierarchical Bayesian MCMC using data for segregating sitespooled from European American (EA) and African American (AA) samples. Shownare the posterior distributions of the mean selection coefficient. The x-axis is givenin units of α = 2Nes, 2 times the haploid effective population size times the fitnessparameter. Four classes of segregating variation are shown: Ultraconserved (UC) el-ements(red), their immediately flanking (UF) regions(blue), SeattleSNPs nonsynony-mous sites(yellow), and SeattleSNPs intronic sites(green). The 95% credible interval forUC elements does not overlap that of any other class of site examined here. The UCdistribution has a wider credible interval than the others because it is derived from thespectrum of a smaller number of segregating sites. The data indicate three-fold strongernegative selection in UC elements than in nonsynonymous sites.
mouse and rat, and hence be excluded from study. This latter bias also applies to polymorphism studies of other types of conserved regions, but had not previously been taken into account at the time that this work was completed. Our probability model is specifically designed to compensate for such bias (Section 2.17), and subsequent work has expanded on this issue [39].
We estimated the effect of the ascertainment bias inherent in the definition of the ultraconserved elements by performing coalescent simulations using the standard neutral model (SNM). For each simulated locus we assigned the locus as "ultra" if a randomly chosen allele matched the ancestral allele. Otherwise, the locus was considered "non-ultra". In Figure 2.4 it can be seen that ascertainment of ultras results in a negative shift in estimates of the selection coefficient, even under a neutral model, but that our correction procedure returns the expected value of our estimates of the strength of selection back to zero.
In addition, I carefully validated the quality of the base calls to avoid other kinds of bias. While singleton heterozygote sites are inherently enriched for sequencing errors, my validation indicates that sequencing errors are not significant in our data (Section 2.7). Furthermore, the difference in DAF spectra between ultraconserved and nonsynonymous sites is evident even if singletons are removed from the study. (Fig- ure 2.1 upper panel.) Finally, I performed a separate analysis showing that my results are not in- fluenced by different strengths of linkage between sites within the separate classes ana- lyzed. (The influence of other unusual regional effects is unlikely since the moderately ML Selection Coefficient Figure 2.4: Correction of Ascertainment Bias of Ultraconserved Elements inEstimates of Selection Coefficient. Coalescent simulations were performed using the stan- dard neutral model (SNM) as described in Section 2.17, and the subset of "ultraconserved" (ultras) was chosen based on the absence of fixed differences in a two-sequence comparison between the outgroup se- quence and a randomly chosen ingroup sequence. Boxplots are shown of Maximum Likelihood estimates of the selection coefficient, in units of 2Nes. If uncorrected, the ascertainment bias for ultras results in an apparent negative selection coefficient for neutrally evolving regions. Applying the correction procedure described in the text removes the effect of the bias and results in the proper zero estimate (corrected) of the selection coefficient.
conserved (UF) bases immediately flanking the ultraconserved regions have a mean se- lection coefficient that is much lower.) To test for any effect of linkage disequilibrium, I applied our analysis to random subsets of the data that should be free of linkage dise- quilibrium as follows. I took 50 random subsets of our data that had at most one SNP per ultraconserved region. I took 50 random subsets of the SeattleSNPs data that had at most one SNP per gene. The distributions of the results across these random subsets are similar to the distributions obtained from the full data sets in the main text, showing that the data are not strongly influenced by linkage disequilibrium (Section 2.15).
Definition of Selection Coefficient The population-effective selection coefficient α = 2Nes, is defined in terms of the haploid effective population size Ne and the fitness parameter s, where the relative fitnesses of an ancestral-allele homozygote, a heterozygote, and a derived-allele homozy- gote are 1, 1 + s, and 1 + 2s respectively. Since the derived allele frequency spectrum is a function of α rather than s alone, it is the more appropriate measure of selection.
Definition of UX, UC, UF regions The ultra conserved (UC) elements as initially described [7] consist of regions at least 200bp in length with 100% identity in the human, mouse, and rat genomes.
The extended ultra (UX) elements are derived from the UC elements by extending the UC regions until the percentage identity among human, chimp, mouse, rat and chicken genomes falls below 85% for 5 consecutive bases. Because several of the UC elements are in close proximity, a single UX element may encompass more than one UC element.
The coordinates of the 461 UX elements are available in Table M1 online [35]. For purposes of comparative analysis, I also define the flanking ultra (UF) regions as the bases in the UX elements that are not in the UC elements.
Sample Populations The sequencing in the UX elements was performed on samples of human ge- nomic DNA from 96 individuals comprising three groups. One group of 24 individuals consisted of a nested subset of the Polymorphism Discovery Resource [14], which we refer to as the human diversity (HUDIV) panel and was included to maximize our dis- covery of human polymorphism in the UX elements, but for which we do not have ethnic information. The second group consisted of 60 individuals from the CEPH Utah sam- ples, 30 of each gender, all of European background (the EA panel). The third group consisted of 12 individuals of African American background, which are also members of the Seattle SNPs PGA panel 1 (the AA panel). All samples were obtained from the Coriell Institute for Medical Research [Camden NJ] and the full list of repository numbers is available in Table M3 online [35]. Except where noted, the analysis was confined to the 72 EA+AA samples.
Selection of Primers To design primers, the UX sequences were extended by 100 bp on either end and then split into overlapping regions of no more than 500 bases to define maximum length amplicons for PCR amplification and sequencing. In one case a pair of UX elements was merged (UX 418,419) after the extension process. To avoid difficulties in the PCR amplification, certain low complexity regions were avoided, such as mononucleotide runs greater than 12 bases, or runs of 50 bases or more containing only one or two nucleotides.
The program primer3 [67] was used to pick PCR primers as close as possible to the specified desired amplicons with melting temperatures near 60 degrees. The list of primer pairs for the 473 amplicons that were successfully sequenced (see Section 2.5) is available in Table M2 online [35]. Of the 461 UX elements covered by the full set of amplicons, 310 were covered by a single amplicon, 143 by two amplicons, 7 by three amplicons and 1 by five amplicons as shown in online Table M1 of UX elements noted The PCR and sequencing reactions for the amplicons were performed by the Washington University Genome Sequencing Center (WUGSC) as follows: PCR was performed in a 10uL reaction containing 5ng of gDNA, 1.2nmol of each (universally) tailed amplification primer, 5.0uL of Amplitaq Gold 2X mix (Applied Biosystems P/N 4327059, Foster City,CA), with glycerol added to a final 8% concentra- tion. Reactions were cycled in a PTC-225 DNA engine (Biorad Laboratories, Hercules, CA) with an initial denaturation step at 96 degrees for 5 minutes, followed by 40 cycles of 94 degrees for 30 seconds, 60 degrees for 45 seconds, and 72 degrees for 45 seconds, followed by a final extension at 72 degrees for 10 minutes. Following amplification, PCR products were treated with 3.7U of Exonuclease I (USB P/N 70073X, Cleveland,OH) and 0.18U of Shrimp Alkaline Phosphatase (USB P/N 70092X), and incubated AT 37 degrees for 30 minutes. The reaction was stopped by incubation at 80 degrees for 15 min- utes. PCR products were sequenced with BigDye Terminator Sequencing Kit(Applied Biosystems P/N 4336943) using either universal forward OR reverse sequencing primers, and analyzed on an ABI 3730XL DNA sequencer.
In order to ensure that any low frequency polymorphisms were correct we established strict quality criteria for the sequencing reads. The goal was to have 85% of the bases in the reads for an amplicon in each direction at or better than a phred quality score of Q35. The final data set analyzed comprised three sets of amplicons which approaced this goal: Set1 consisted of 387 amplicons for which 80% or more of the bases in both directions were at or above Q35. Set2 consisted of 54 amplicons with at least 80% Q35 in one direction and at least 75% Q35 in the other direction. Set3 consisted of 32 amplicons for which multiple reads were supplied in each direction, in order to confirm that the cause of low quality was generally insertion/deletion heterozygosity. The latter destroys the quality of the sequence read from amplified genomic DNA at the point of heterozygosity in each direction.
The final list of 473 amplicons shown in the online Table M2 of primers noted above touched a total of 362 UX elements and completely covered 332 UX elements, which is indicated by the "All" column in online Table M1 of UX elements. Unless otherwise stated, the analysis was carried out on the smaller list of 332 completely covered UX elements of which 227 were covered by a single amplicon, 103 by two amplicons and 2 by three amplicons.
Processing of Chromatograms The reads for all amplicons in a given UX element were processed together.
First the reads were aligned to the genomic reference sequence defining the amplicons and the phred quality calls were made using the cross-match/phred/phrap/consed tools from the University of Washington [22, 21, 29]. Then the polyphred tool, also from the Univ. of Washington [50] was used to determine the polymorphic positions in the UX elements and, for each sample, its genotype (combination of two alleles) at each polymorphic position. The polyphred "-rank 1" option was used to specify the most stringent specification for polymorphism calls (see Section 2.8), and the "-source" option was used to enable polyphred to use all of the reads for a given sample in determining the genotype for that sample. Other parameters were left at defaults. In particular, the "-quality 25" and "-window 20" default values were used by polyphred "to determine the extent of excluded, or trimmed, regions at the ends of sample sequences", in the words of its documentation.
Validation of Singletons Because the downstream analysis was critically dependent on the allele fre- quency spectra, I decided at an early stage of the project to validate a sample of the heterozygote polymorphisms found in only one sample. The heterozygotes are the most difficult for polyphred to call. Furthermore, finding them in only a single sample means that they lack intrinsic confirmation in another sample. At this stage I was still con- sidering polyphred polymorphism calls down to (possibly low quality) rank5, because I did not know if I would find many SNPs in the UX elements (see Section 2.8). Of those initially found, forty singleton heterozygote polymorphisms among the HUDIV and AA set of samples were selected for independent resequencing at UC Santa Cruz as follows: An independent set of the sample DNA was obtained from the Coriell Institute (see Section 2.3). The same amplification primers as used by WUGSC for the appro- priate sequences were acquired [Invitrogen Corporation, Carlsbad, CA], except that the universal sequencing tails were not added to the primers. PCR was performed using the high fidelity PfuUltra polymerase [Stratagene Corporation, La Jolla, CA] per manufac- turers recommendations, but no attempt was made to optimize the PCR conditions.
Sequencing of each PCR product was performed by the UC Berkeley DNA Sequencing Facility using each of the amplification primers.
To enable polyphred to make polymorphism calls for the putative heterozygote singleton samples, 10 of the WUGSC reads from the EA sample, which were necessarily homozygous at the position of interest in the same UX element, were added to the sequenced sample and the polyphred analysis was run.
Thirty-one of the 40 PCR reactions yielded a good quality single band when visualized on an agarose gel. For one of these, the original polyphred heterozygote call from the WUGSC data was a low quality (rank 4) polymorphism call and inspection of the original WUGSC chromatogram showed that it was based on a very poor quality read from a single strand. It was therefore excluded from the validation set and as discussed in Section 2.8 was not included in further analysis.
Thus there were 30 validation samples with sufficiently good quality in the sequences to make base calls. In 29 of these there was a perfect match to the singleton heterozygote seen in the WUGSC read.
In only one case the WUGSC chromatogram showed an apparent heterozygote while the UC sequenced chromatogram showed a homozygote with the same alleles as the other samples. I thus conclude that the worst case error rate of the polymorphism calls in the WUGSC reads is likely to be less than 5%.
Tuning the Polymorphism Rank Parameter The polyphred program used to make polymorphism calls has a "rank" option which can be tuned for more stringent calls. Since heterozygote reads in a diploid DNA sample have an inherently weaker signal for the two alleles at the heterozygous locus, such basepairs as well as the immediately flanking basepairs tend to have lower quality calls from the chromatograms. The most stringent value of the rank parameter is 1, while the default is 3. Since I originally suspected that polymorphism in the ultraconserved regions would be rare, I started with the rank parameter set to 5, to be sure to find all potential polymorphic sites. I quickly found that this led to polymorphic calls in lower quality sequence, often with more than two distinct alleles called at a basepair.
Even at rank4, there were many such calls that appeared questionable upon visual inspection of the chromatograms. Therefore, I performed the following test on a preliminary set of the data. I first excluded UX regions that had any calls at rank 4 with more than two alleles at a basepair. For the remaining set of UX regions, I ran polyphred with rank 1, 3, and 4. The resulting number of segregating sites that were called in this experiment were as follows: 254 (rank1), 277 (rank3), and 298 (rank4).
Since the difference between rank3 and rank1 was less than 10%, and since using rank1 allowed me to include more UX regions (since they no longer had more than 2 alleles at any sites) I used rank1 for all further analysis.
UC vs. UF Quality Comparison Because one of my conclusions is that the core ultraconserved elements (UC) are under stronger selection than their immediately flanking (UF) regions (thus control- ling for any potential bias due to genomic locus) it is important that the comparison between UC and UF allele frequencies be based on data of similar quality. It may be supposed that since the UF bases are generally near the beginning or end of amplicons they may be of lower quality, leading to a higher rate of false positives. This supposition is mitigated by several factors. As noted in Section 2.4 the amplicons were designed to be no longer than 500 bases to ensure that the end of the reads would not be of diminished quality. Also, the PCR primers were selected from a region that extended beyond the defined UX element. Finally, as noted in Section 2.5, the PCR primers were appended with universal tails that were used in the sequencing reactions, so that the beginning of the high quality portion of each read would include all bases immediately after the PCR primers.
As a validation of these factors, I analyzed the distribution of the quality scores assigned by polyphred to the UC and UF bases. I excluded those bases in any read for which a base call was not made since such a base can never lead to a false positive polymorphism. This is a conservative approach since it does not exclude other bases with very low quality that might also never be used to call a polymorphism. I also excluded bases that were trimmed by the polyphred program using the "quality" and "window" parameters. I derived quality probability distributions (and the cumulative distributions) for UC and UF regions, both for all valid bases as well as only those which actually were called as segregating sites (Figure 2.5 and Figure 2.6). It can be seen that the UC and UF distributions track each other very closely and that the segregating site distribution is a representative subset of the all-base distribution. The cumulative distributions and the boxplots in Figure 2.6 indicate nearly equal medians and while they do show that the UF regions have more very low quality bases, the latter still have better than 80% of bases above quality 35, while the UC bases have better than 90% above this quality level. (The phred quality score is 10 times the negative common logarithm of the probability of an error in the base call. For example, a score of 40 means less than 10−4 chance of error.) All valid bases
Valid Segsite bases
cumulative probability cumulative probability Figure 2.5: Distributions of quality scores for UC and UF regions. Left panels show probability mass (upper panel) and cumulative (lower panel) distributions of polyphred quality scores for all base positions in 332 UX elements, for all reads (one read for each DNA strand times 96 samples with some additional amplicon overlap) in which a valid base call was made by polyphred.
Right panels are restricted to positions which were called as polymorphic (segsites) in the pooled set of all 96 samples. Quality score assignment is discontinuous and points are only plotted at quality values with non-zero counts.
Figure 2.6: Boxplots of quality scores for UC and UF regions. Boxplots are shown for the quality scores for all base positions in 332 UX elements, and for positions which were called as polymorphic (segsites), as described in Figure 2.5. The median quality values are nearly the same for UC and UF regions although the UF region are skewed towards lower quality values.
I further note (Figure 2.2) that it is the higher derived allele frequency poly- morphisms that distinguish the UF spectrum from the UC spectrum. To check whether these might be due to the slightly lower quality in the UF regions, I manually examined the chromatograms for the the 53 segregating UF sites with derived allele count at least 10 (out of 144) in the pooled EA+AA sample, examining about 5 bases on each side of the site. I found that 32 of these 53 sites had good quality reads from both strands.
An additional 6 sites had good quality reads from one strand and generally fair quality reads from the other. There were 13 sites that had good quality reads from only one strand with the other strand either missing or of poor quality. Only 2 sites had fair quality reads on both strands.
I conclude that any bias due to the difference in quality between UC and UF regions had little impact on my quantitative results comparing UC to UF elements.
Sequence Analysis In generating the population genetics statistics, the base calls for the reads were filtered by the polyphred output. Any bases in a sample that disagreed with the reference genome sequence, but which were not tagged as polymorphic (at rank 1) by polyphred were converted to N, and ignored in further analysis. For a particular position to be included in the analysis (whether polymorphic or not) it had to have a minimum of 50% of the samples with a base call of A, C, G or T. Thus positions with many Ns (either due to low quality or the filtering just mentioned) or many indels were excluded.
Furthermore, for calculating the derived allele frequencies or minor allele frequencies at polymorphic positions only the A, C, G or T alleles were counted, thus excluding indels from the analysis. Finally, a check was included to verify that only bi-allelic polymorphisms were found. For each of the subsamples, and for the UC and UF regions separately, the counts of basepairs remaining after the above filtering, and the number of segregating sites found, is listed in Table 2.1.
For determining the derived allele frequency at the segregating sites, a whole genome 3-way alignment of human, chimpanzee, and rhesus macaque was used. This was generated by the multiz program [10] using the March 2006 human assembly (NCBI Build 36.1, UCSC browser hg18), March 2006 chimp assembly (Chimpanzee Sequenc- ing and Analysis Consortium Build 2 Version 1, UCSC browser panTro2) and Jan 2006 rhesus assembly (Macaque Genome Sequencing Consortium v1.0, UCSC browser rheMac2). This particular alignment was made with stringent synteny requirements to avoid alignments to paralogs and pseudogenes. Because of lack of complete coverage of the genomes, only 315 of the 332 UX elements analyzed had full 3-way alignments. The results based on derived allele frequency spectra were derived from this subset, which is indicated by the "Daf" column in the online Table M1 of UX elements noted above.
Since only bi-allelic polymorphisms were considered, the derived allele was determined as the one not equal to both chimp and rhesus at the aligned position. If chimp and rhesus and one of the human alleles did not all agree, the position was ignored for pur- poses of derived allele analysis. For each of the subsamples, and for the UC and UF regions separately, the counts of basepairs included and the number of segregating sites found in the subset of 315 UX regions is listed in Table 2.2.
A set of population genetics summary statistics for various subsamples is shown in Table 2.3. In calculating these statistics the requirement for 50% of samples to be A, C, G or T was applied to each subsample.
The derived allele frequency spectra for the pooled set of European American (EA) and African American (AA) samples are shown in Figure 2.2.
Table 2.1: Segregating Sites Counts for 332 UX Fully Sequenced Elements.
Sample Size: maximum number of chromosomes in the subsample, which is twice the number of indi- viduals in the subsample. Basepairs: filtered as described in the text.
Table 2.2: Segregating Sites Counts for 315 UX Elements with Chimp andRhesus Alignments. Notes as in Table 2.1.
Seattle SNPs Comparative Analysis For comparative purposes, the Seattle SNPs PGA polymorphism data was downloaded [SeattleSNPs. NHLBI Program for Genomic Applications, SeattleSNPs, Seattle, WA (URL: http://pga.gs.washington.edu) July 11, 2006]. I note that the quality of this data is described at their web site such that sequence quality greater than 30 is used for polymorphism detection, and that all heterozygote singletons are re-amplified and re-sequenced for confirmation.
This is comparable to the quality for my data discussed in Section 2.9.
From the available data, a subset of 211 genes that were included in the analy- sis is available in Table M6 online [35] and comprise a set that were all sequenced in the same set of samples, referred to as PGA panel 1. This panel of 23 CEPH Utah Euro- pean American samples and 24 African American samples includes the 12 AA samples sequenced for the UX elements and allows limited direct comparisons of the estimates of the population genetic parameters. As in the UX element analysis, polymorphisms were ignored unless they were simple bi-allelic base substitutions.
From information in the Genbank format file for each of the above genes, the subset of bases actually scanned was determined as well as the subsets of coding (cds), non-coding, or intronic bases. Within the cds bases, a subset of 321 of the 633 polymorphisms were assigned as nonsynonymous as follows. Within the UCSC Genome Browser the track of dbSNP build 125 polymorphisms [73] maps as nonsynonymous those SNPs which are in the set of knownGenes [31] and can be unambiguously assigned to a codon with polymorphic amino acid alleles. As a test, from the full set of 1156 bi-allelic cds Seattle SNPs in all genes downloaded (not just the set of 211 genes), 998 of the coordinates were found within knownGenes and also had an assigned dbSNP "rs" As was done for the UX elements, the derived allele in the Seattle SNPs was defined by mapping the corresponding chimp and rhesus macaque base, and requiring that they be equal to each other and to one of the alleles at the bi-allelic human SNP.
The derived allele frequency spectra were generated from an aggregation of all such polymorphic bases across the 211 genes noted. The same tools as for the UX elements were then applied to derive estimates of selection coefficients. To reduce the compu- tational burden of a high number of segregating sites, in the case of intronic sites, the MCMC method was applied to a subset in which 3 randomly selected segregating sites per gene were included.
For the estimates of population genetics parameters θπ, θW , and Tajima's D, the calculations were performed separately for each of the 211 genes, and then aggregated by weighting each gene's contribution by the number of base-pairs scanned for the gene in the relevant category. For the nonsynonymous case, the method of Nei and Gojobori [49] was used to determine the number of potential nonsynonymous sites among the scanned bases.
The results of these calculations are found in Table 2.3. The derived allele frequency spectra for the pooled set of European American (EA) and African American (AA) samples are shown in Figure 2.2.
Hierarchical Bayesian Model [AK] Assuming an infinite sites Wright-Fisher model, with no linkage among sites, and no interference among mutations, the stationary distribution of the frequency p of a newly arisen mutation under selection can be expressed as 1 − e−α(1−p) ([24, 84]). This represents the population stationary distribution of allele frequencies as a function of α which itself is the product of the haploid effective population size and the selection coefficient of the new mutation (α = 2N s). To be applicable to samples, we add a layer of binomial sampling to express the density of observing derived alleles segregating in i out of n individuals, and define the function pi(1 − p)n−iφ(p α)dp [70]. From here, Williamson et al. [81] derived an expression for the probability of a SNP frequency, conditional on it segregating in the sample as Pn−1 F (j n, α) Assuming that each new mutation k is associated with its own selection coefficient αk, the parameter α becomes a vector of selection coefficients. The likelihood function describing the probability of the data given this vector, conditional upon the sample sizes of each SNP, follows trivially as the product of the individual SNP probabilities given in Equation 2.3.
In our hierarchical Bayesian model, we assume that each selection coefficient, αk, where k indexes the individual segregating sites, is drawn independently from a genomic region- wide normal distribution with mean µ and standard deviation σ.
framework, we treat the parameters of our model (the vector α and the scalars µ, σ) as random variables with an underlying prior distribution. Using a prior distribution along with the likelihood function that follows from Equation 2.4 we can then describe the joint posterior distribution of our model given the data, P (α, µ, σ Data).
model is said to be "hierarchical" in that µ and σ are hyperparameters, which control the distribution of other parameters in the model (the αks). Symbolically then, the posterior of our distribution is P (Data α)f (α µ, σ)g(µ σ)h(σ) P (α, µ, σ Data) = R R R P (Data α)f (α µ, σ)g(µ σ)h(σ)dαdµdσ where P (Data α) is the likelihood function of the data, conditional upon the selec- tion coefficients α and the sampling, and f (α µ, σ) is the assumed genomic region-wide normal distribution of selection coefficients. The other prior distributions are chosen out of convenience in computation such that g(µ σ) is itself normally distributed about the mean µ, and h(σ) is assumed to be gamma distributed. These additional priors were tuned to assure good acceptance rates and rapid convergence as described in Sec- The distributions obtained for µ for the UC and UF sets of segregating sites are displayed in Figure 2.7. Separate curves are shown for different population subsamples.
We expect the distributions to vary by subsample due to differences in Ne and demo- graphic history. Nevertheless, for all subsamples, the UC regions have strong negative selection coefficients, with essentially no overlap between the UC and UF distributions.
The distributions obtained for µ using the pooled set of European American (EA) and African American (AA) samples for our data (UC,UF) and the Seattle SNPS data (nonsynonymous,intron) are displayed in Figure 2.3. The Maximum A Posteriori estimate and 95% credible interval for µ in various samples are shown in Table 2.4.
MCMC Implementation and Convergence [AK] As the joint posterior of the model, P (α, µ, σ Data), is analytically intractable, we use Markov Chain Monte Carlo (MCMC) to sample from this distribution. The key is to define a Markov Chain whose stationary distribution is P (α, µ, σ Data). To do this we use the Metropolis-Hastings algorithm, whereby at each iteration a new parameter set Θ? is proposed from some current parameter set Θ = [α, µ, σ], and is accepted with UC ALLUC EA+AAUC AAUC EAUF ALLUF EA+AAUF AAUF EA posterior probability density mean selection coefficient Figure 2.7: Posterior Distributions of the mean selection coefficient. Results of hierarchical Bayesian MCMC using data for segregating sites from the indicated subsamples. The x-axis is given in units of α = 2Nes, 2 times the haploid effective population size times the fitness parameter.
For each subsample two classes of segregating variation are shown: UC regions(red), UF regions(blue).
ALL: full set of 96 samples in the current study. EA: European Americans. AA: African Americans.
P r(accept) = min[1, In this expression f (Θ? Θ), which can be tuned to optimize the acceptance rate, repre- sents the probability of proposing the new parameter set Θ? from the old parameter set Θ, while f (Θ Θ?) is the converse probability. This ratio f(Θ Θ?) is commonly referred to as the Hastings ratio. The first two terms in the overall acceptance ratio are the like- lihood and prior ratios respectively. If Θ? is accepted, the new parameters are recorded and serve as the parameters of the next iteration. Otherwise the parameters remain at Θ for the next iteration.
Typically a large number of iterations of the algorithm are run to ensure that the Markov Chain has reached stationarity. For each dataset analyzed, we ran 9 separate chains from overdispersed initial parameter values for 50,000 iterations. An example of such a run of 9 chains is seen in Figure 2.8.
Convergence of our MCMC was monitored using the multivariate analog to Gelman's potential scale reduction factor ˆ R [12], which uses the independence of mul- tiple chains to assess convergence by combining terms corresponding to the variance between chains with those corresponding to the variance within chains. An example of convergence using this metric is given in Figure 2.9, where one can see the scale reduction factor quickly converging to 1.0. Once convergence was established, the first 10,000 iterations of each MCMC chain were considered burn-in and discarded, while the

remainder were retained for use in estimation.
Figure 2.8: MCMC output from one dataset. Nine independent chains are run from overdispersed starting points and are shown here in individual colors. Displayed are the joint posterior probability ("postProb"), µ ("X2Ns mean"), and σ ("X2Ns sd"), over the 50,000 iterations for the case of UC regions using EA+AA pooled samples. Shown in the right hand panel are the marginal distributions of each of the parameters. Convergence of our chains can be seen here by the relatively consistent bands traced by the model parameters among chains.
Maximum Likelihood Estimates [AK] The Hierarchical Bayesian MCMC model described in Section 2.12 treats the mean selection coefficient µ as a random variable and allows calculation of its expected last iteration in chain last iteration in chain last iteration in chain Figure 2.9: Convergence plots for MCMC simulations. Shown here is the reduction in the [12] scale reduction factor ("shrink factor") ˆ R over the course of our MCMC iterations for the case of UC regions using EA+AA pooled samples. Values close to 1.0 indicate convergence of the MCMC to the posterior distribution of our parameters. Plot labels as in Figure 2.8.
value and variance. A less computationally intense and perhaps more conventional approach can be used to derive the Maximum Likelihood (ML) point estimate of the selection coefficient α where the likelihood of the data is, as before, the product of the individual SNP probabilities given in Equation 2.3 but the SNPs are assumed to be independent and identically distributed with a common selection coefficient α. That is, we find the value of α that maximizes the likelihood Following the methods of [13] we have numerically maximized Equation 2.7 to determine these ML estimates for our various genomic regions and population sub- samples. The results comparing the ML estimates to the MAP estimates from the full Bayesian model are shown in Table 2.5. It can be seen that the agreement between the two methods is quite good so that our conclusion about the strength of selection on the ultraconserved elements is not dependent on our Bayesian methods.
Table 2.5: Estimates of the selection coefficient using Bayesian and MaximumLikelihood methods MAP: Maximum A Posteriori estimate for mean value of selection coefficient based on hierarchical Bayesian MCMC. ML: Maximum Likelihood point estimate for the selection coefficient. Other symbols as in Table 2.3.
Effect of Linkage Disequilibrium To investigate the possibility that linkage disequilibrium (LD) had an effect on the derived allele frequency spectra, and hence my estimates of the selection coefficients for the categories of sites examined, I performed calculations on subsets of the segre- gating sites found in the pooled EA and AA samples analyzed above. For the Seattle SNPs data, I chose 50 random subsets of the nonsynonymous and intron segregating sites such that each subset had at most one segregating site per gene. For the UC and UF sites I chose 50 random subsets such that each subset had at most one segregating site per UX element. Thus the segregating sites in any of these subsets should have no LD. For the UC sites I also chose 50 random subsets containing the same number (105) of segregating sites as in the one-per-UX subsets of UC sites, but this time without regard to the UX element of a site.
For each subset I calculated the ML estimate of the selection coefficient as described in Section 2.14. The distribution across the subsets for each class is shown in Figure 2.10. The median values of the subsets (listed in the caption of Figure 2.10) are very close to the ML values for the EA+AA pooled samples (shown in Figure 2.10 and listed in Table 2.5) with the largest effect being about a 15% reduction in the estimated strong negative selection coefficient for the UC category. But this category has the largest variance and the interquartile range of its subsets is completely consistent with the its distribution in Figure 2.1. I am thus confident that my essential conclusion about the selection coefficients in the different categories is not an artifact of LD.
ML Selection Coefficient Figure 2.10: Selection Coefficient Estimates without Linkage Disequilibrium.
Boxplots of the distributions of Maximum Likelihood (ML) estimates of the selection coefficient, in units of 2Nes, derived from 50 subsamples (for each category) of the segregating sites in the pooled EA+AA samples are shown. The NonSyn and Intron subsamples include only one SNP per gene in the Seattle SNPs data set. The UF and UC-noLD subsamples include at most one SNP per UX. The UC-rand subsamples had the same number of SNPs as UC-noLD, but were chosen without replacement from UC SNPs without regard to UX. The ML estimates for the full set of EA+AA samples in each category are shown as thin red lines. The median values (-5.2, -4.4, -1.5, -1.3, -0.16) for the subsets are consistent with the distribution of values in Figure 2.3, indicating that the latter are not strongly dependent on linkage disequilibrium in the respective regions of segregating sites.
Ascertainment Effects [AK] Ultraconserved elements of the human genome were identified through the criterion of 100% sequence homology among species.
Since polymorphisms within species are apt to be confused with fixed differences between species when single se- quence comparisons are used, one would expect ultraconserved elements to contain fewer polymorphisms than non-ascertained genomic regions even under the neutral model. Furthermore, one would expect those polymorphisms that are present in ul- traconserved elements of the genome to be segregating at lower frequencies than those in non-ultraconserved regions, since intermediate and higher frequency polymorphisms are more likely to be mistaken for fixed differences between species. Since our estimation of selection coefficient uses information from the frequency spectrum of segregating poly- morphism, these biases might mimic the effects of selection on ultraconserved regions of the genome.
To quantify the strength of this ascertainment bias in our data, we performed extensive coalescent simulation of the ultraconserved element identification process, to examine the extent to which selection of ultraconserved elements alone can skew the site frequency spectrum under neutral models. We used Hudson's "ms" program [32] to perform the simulations under the standard neutral model (SNM). Our procedure con- sisted of simulating 100,000 unlinked genomic regions from 96 individuals (representing our human samples) and 1 outgroup lineage (representing a chimp sequence), with a species divergence time of 5 units of 4Ne generations (about 5 million years assuming Ne = 10,000 and a 25 year generation time), and a fixed value of θ (4Neu = 0.5).
We then split these 100,000 unlinked regions into those that were "ultraconserved" vs.
"non-ultraconserved" by comparing our outgroup sequence to one randomly selected individual from our ingroup and finding those regions that had zero fixed differences in the two-sequence comparison.
Distributions of Tajima's D [75] for our two classes of region are shown in the left panel of Figure 2.11. The bias imposed by selection of the ultraconserved genomic regions on Tajima's D results in a shift in the frequency spectrum towards rare alleles for ultraconserved elements but the bias is quite small. Under the standard neutral model we do not see values of Tajima's D that are as extreme as we observed in our data (Table 2.3). Other demographic models incorporating population expansions yielded similar results (data not shown).
Additionally we estimated the strength of selection α using ML estimates as in Section 2.14, for the separately pooled sets of simulated "ultraconserved" and "non- ultraconserved" polymorphisms. These simulations were repeated 10,000 times for the standard neutral model (SNM) yielding the distributions shown in the right panel of (Figure 2.11).
A fairly large difference between simulated ultraconserved and non- ultraconserved sequences is observed. Ascertainment of ultras results in a negative shift in estimates of the strength of selection, even under neutrality. In order to correct for this ascertainment bias, we applied the procedure described in Section 2.17.
ML Selection Coefficient Figure 2.11: Effect of Ascertainment Bias of Ultraconserved Elements onTajima's D and Estimates of Selection Coefficient.
Coalescent simulations were performed using the standard neutral model (SNM) as described in the text, which were then split into "ultraconserved" (ultras) and "non-ultraconserved" (non-ultra) subsets based on the absence/presence of fixed differences in a two-sequence comparison between the outgroup sequence and a randomly chosen ingroup sequence. Left panel shows boxplots of Tajima's D statistic, indicating that scertainment of the ultraconserved elements has only a weak effect of biasing Tajima's D downward. Right panel shows box- plots of Maximum Likelihood estimates of the selection coefficient, in units of 2Nes. If uncorrected, the ascertainment bias for ultras results in an apparent negative selection coefficient for neutrally evolving Correcting for Ascertainment Bias [AK] As noted in Section 2.16, identification of the ultraconserved elements on the basis of no divergence between species will impact the expected site frequency spec- trum at those loci, even under the neutral model. To obtain accurate estimates of the strength of selection at UC regions we modified our likelihood function (Equation 2.3 and Equation 2.4) to directly correct for this ascertainment bias. Following the general framework of Nielsen et al. [51], we assume that our ascertainment was performed in a subsample, size d, of our final sample, size n, where the derived allele frequency at segregating site k was ik, such that the probability of ascertainment (probability of choosing d ancestral alleles) is In our case d = 1, corresponding to sampling the ancestral allele at our single genomic reference sequence. With this probability in hand, using Bayes rule we can write down the ascertainment corrected version of Equation 2.3 (suppressing the dependence on sample size, but emphasizing that the bias is dependent on the site k). The probabil- ity of observing a SNP segregating with derived allele frequency ik, conditional upon ascertainment and the strength of selection α is P r(ik α)P r(Asck ik, α) P r(ik Asck, α) = where the denominator is simply the normalization factor P r(j α)P r(Asck j, α).
Our corrected likelihood function can then be expressed as P (Data Asc, α) = This ascertainment corrected likelihood function was tested using the coales- cent simulation scheme described in Section 2.16. As can be seen in Figure 2.4, this procedure returns the expected value of our estimates of the strength of selection back to zero. Subsequently, all estimations done for UC regions, both Bayesian and Maximum Likelihood, use this ascertainment corrected formulation.
A comparison of the ML estimates for the ultraconserved regions with and without correction in various samples is given in Table 2.6. The correction reduces the estimate for the UC regions by about 10-20%.
Table 2.6: Ultraconserved Element Ascertainment Bias Correction in Esti-mates of the selection coefficient. Maximum Likelihood point estimates for the selection coefficient in the ultraconserved regions with (UC-corr) and without (UC-uncor) correction for the as- certainment bias. The correction reduces the estimate by about 10-20%. Other symbols as in Table 2.3.
Evolution of Human Accelerated Regions is GC-Biased As noted in the Introduction, I enriched the genomic DNA from 11 individu- als among the Yoruba from Ibidan, Nigeria (YRI samples) for 40kb neighborhoods of the top 49 Human Accelerated Regions [59] (HARs) (hereinafter "harseq1-49"), and 13 similar control regions not containing HAR elements (hereinafter "ctlreg50-62") using a microarray hybridization technique. Using ABI SOLiD [6] high throughput sequenc- ing technology I obtained sufficient coverage in the target regions of the resulting short (35bp and 50bp) sequencing reads to restrict my analysis to genotype calls at positions where I had at least 35-fold coverage for an individual, to ensure accurate genotyping.
I determined the frequency of the derived (non-ancestral) allele in my set of 22 chro- mosomal samples for all the resulting segregating sites (i.e. sites where not all samples have the same allele).
I analyzed these segregating site frequencies in several ways. First, I compared the frequency spectra of two subsets of my segregating sites: those comprising W2S mutations (where the ancestral allele is either A or T, and the derived allele is either G or C) versus the S2W mutations. Next, I compared the ratios of these different classes of mutations to the same ratios for fixed substitutions that have arisen on either the human or chimp lineages since our common ancestor ∼5 million years ago. For both of these analyses I tested the strength of my results across the full scale of my regions, and also performed the tests on the data pooled across my 49 genomic regions.
Finally, I examined the pattern of spatial variation of derived allele frequencies in search of evidence for a selective sweep. Results for harseq regions and ctlreg regions were compared to each other and to a set of 62 genic regions resequenced in the same 11 YRI individuals by the Seattle SNPs project [4].
My key conclusions reinforce the notion that a bias in fixation of GC basepairs is at play in the HAR neighborhoods. The use of the present tense ("is at play") in the previous sentence is intentional, for I have two significant results. On the one hand, I confirmed the historical GC-bias for fixation, finding in 10 of the 49 HAR neighborhoods that fixed differences are more likely than polymorphic sites to show this bias. But in my more novel result I also found that there is a similar GC-bias towards higher derived allele frequencies at polymorphic sites alone. The high derived allele frequencies at these GC-biased SNPs make them likely candidates for eventual fixation. I found this ongoing bias in 11 cases, only 1 of which also shows historical GC-bias. Thus, almost half of HAR regions (20) are currently undergoing, or have historically undergone, biased fixation of GC alleles. This pattern strongly suggests that selectively neutral forces, such as biased gene conversion, have helped to shape many of the genomic regions containing HARs and could have influenced the fixation of a large number of GC alleles in the HAR I also used my resequencing data to search for signals of a recent selective sweep, which could have indicated that one or more of the HAR substitutions had been subject to recent positive selection in the human population. In that analysis, I found that only weak signals of that kind remain, possibly due to millions of years of decay.
It may be noteworthy that 3 of the 5 regions with those signals are also significant in one of the two GC-bias tests.
The following sections provide more details of these results and describe the methods used to derive them. In this work I collaborated with Andrew Kern who implemented the coalescent simulations to determine p-values for the SweepFinder test described below. Another collaborator in this work was Katherine Pollard who provided the substitution rate matrix used in simulations to validate the p-values of the MK test described below.
Results of HAR Neighborhood Analysis Weak-to-Strong Mutations are Being Swept to Higher Derived Allele Frequencies When the HARs were first described, a strong W2S substitution bias was noted in the human-specific substitutions in these elements [59, 60]. This bias was extremely pronounced in HARs 1,2,3, and 5, but also noticeable as a general trend in the entire set 1-49. This evidence suggested that biased gene conversion (BGC) could have had an historical role in the evolution of the HARs. Here I analyze my list of segregating sites in the 40kb HAR neighborhoods to determine if such bias is still ongoing in the human population. In each region, I separately computed the derived allele frequency spectra for the W2S mutations and the S2W mutations. I then tested for an offset in the spectra between the two categories with a two-sided Mann Whitney U (MWU) test.
This test has been shown to have good power to detect fixation bias [3].
I found a significant (p ≤ 0.05) difference in 11 out of 49 harseq regions (Table 3.1). In all 11 significant harseq regions, the offset was for the W2S mutations to be segregating at higher derived allele frequencies than S2W. This implies that regardless of the rate of introduction of W2S or S2W mutations, it is the W2S mutations that are more likely to reach high frequency and eventually fix in the human population. This is certainly consistent with a mechanism of gene conversion that favors selection of G or C alleles from a heterozygote or some other selective force generally favoring higher GC content. The novel features of this result are that it indicates that this process is ongoing and not confined to the core 100–400bp HAR elements.
This ongoing W2S fixation bias distinguishes the harseq regions from ctlreg regions and Seattle SNPs regions. Significant MWU tests were observed at none of ctrlreg50-62 (Table A.2) and five out of 62 Seattle SNPs regions (Table A.3), one of which has higher derived allele frequencies in S2W compared to W2S mutations. Applying the MWU test to simulations of a neutral coalescent model as described in Section 3.2.7 showed that the p-values from this test accurately reflect the fraction expected by chance from a neutrally evolving locus.
The two harseq regions with the greatest offset were harseq21 and harseq34 (Figure 3.1). Note that across these two 40kb regions, the ratio of W2S to S2W segregat- ing sites is not extreme; it is the W2S shift towards higher frequency in the population that is significant. These ratios are consistent with the smoothed ratios reported in the top several thousand conserved candidate HAR elements [59] even though my 40kb regions do not comprise largely conserved regions.
It is natural to theorize that BGC will be a stronger driving force in areas of high recombination and studies have shown there to be a good correlation with the male recombination rate in particular [17]. I examined the recombination rates in the enclosing 1Mb windows as determined by the deCODE project [41]. Harseq21 is an outlier in that it is contained in a genomic region of extremely high recombination rate (male 4.29 cM/Mb, sex-averaged 3.43 cm/Mb, in contrast to genome-wide averages of 0.93 cM/Mb and 1.29 cm/Mb respectively). But this is not true of harseq34 (0 male and 1.42 cm/Mb sex-averaged). For the remainder of the regions with a significant p-value harseq21 segregating sites spectra. AT to GC vs. GC to AT mutations
fraction of sites derived allele frequency (count of 22) harseq34 segregating sites spectra. AT to GC vs. GC to AT mutations
fraction of sites derived allele frequency (count of 22) Figure 3.1: Frequency offset of weak-to-strong vs. strong-to-weak mutations.
MWU test is strongly significant for harseq21 (upper panel) and harseq34 (lower panel). This reflects the fact that the derived allele frequency spectrum for weak-to-strong mutations (dark bars) is offset towards higher frequencies compared to strong-to-weak mutations (light bars). N: count of segregating sites of the indicated category in the region.
on the MWU test, the rates vary. An additional (not unrelated) factor that has been strongly correlated with biased substitutions is chromosomal position near telomeres [17]. With the exception of harseq1 this is not the case for the regions with significantly shifted W2S spectra (Table 3.1).
I also performed the MWU test for the shift in W2S sites toward higher fre- quencies after pooling all the segregating sites in my 49 harseq regions, and found a p-value < 10−10. By contrast, the test was not significant (p = 0.26) for the pooled data in my 13 control regions, thereby controlling for possible systematic bias in my sequencing and genotyping techniques. I thus conclude that in many of the neighbor- hoods of the top 49 HARs there is an ongoing force driving W2S mutations to higher frequency in the human population.
Weak-to-Strong Mutations are More Likely to Have Become Fixed Differences Since the HARs were essentially defined based on fixed differences between the human and chimp reference genomes in otherwise strongly conserved elements [59], I compared such human/chimp fixed differences to the segregating sites in my human samples. My set of fixed differences was based on high quality base calls from the reciprocal best alignments [38] of human and chimp genomes. I further restricted this list to the locations within my regions for which I had the above-mentioned 35-fold coverage for an individual in my sample. Finally, I removed from this initial fixed difference list those positions that I found to be segregating in my samples, or that appeared in the dbSNP129 database [71] (see Section 3.2.6). The latter two filters removed 6.7% of the fixed differences at high coverage positions. Since I do not have information on sites that are segregating in the chimp population, I could not remove those, but would expect the number to be similarly small.
I separated the mutations in my segregating site set into the categories: W2S, S2W, and neither. I similarly divided the set of fixed differences, regardless of whether the substitution occurred on the chimp or human lineage. As in reference [17], I per- formed a variant of the McDonald-Kreitman (MK) test to compare the W2S:S2W ratios in the sets of mutations and the sets of substitutions as described in Section 3.2.6.
I found a significant (p ≤ 0.05) difference between the substitution patterns of segregating versus fixed sites in 11 of the 49 harseq regions (Table 3.2). In all but one (harseq39) of these 11, the fixed substitutions had relatively more W2S mutations (compared to S2W) from the ancestral form than did the segregating sites. Four of the 11 fell in the 40kb neighborhoods of the top 11 HARs, and indeed the strongest result (p = 0.00015) was for harseq1. This is not surprising, since the HAR1 element has 18 fixed differences, all W2S [60]. By contrast, none of the ctlreg regions and nine out of 62 Seattle SNPs regions had a significant p-value on this test (Tables A.2 and A.3).
All of the nine significant Seattle SNPs regions had a higher W2S:S2W ratio in fixed differences than in segregating sites. Thus, the harseq regions have a much stronger signal for historical fixation bias than my control regions and a somewhat stronger signal than the genic Seattle SNPs regions. Applying the MK test to simulations of a neutrally evolving primate phylogeny (see Section 3.2.7) showed that the p-values from this test accurately reflect the fraction expected by chance from a neutrally evolving I also recapitulate and expand the finding [59] that this bias towards W2S fixa- tion is associated with telomeres, since 7 of the 11 significant regions under the MK test were found either in the karyotype band containing a telomere or the one immediately adjacent. (This count includes the two cases of harseq19 and harseq36 from chromosome 2 that fall adjacent to the ancestral telomeric fusion event at 2q14.1.) Although many of the 11 regions (including ones near telomeres) have elevated recombination rates, it is also worth noting that 5 of the 11 are in regions with much lower than average male recombination rates (including the two near the chromosome 2 fusion site, and harseq11 One noteworthy negative result from the MK test, (and the MWU test as well) is harseq2. It had been noted [59] that the core HAR2 element showed a strong bias towards W2S fixations, and that this extended to a region of ∼1kb. Here I find no significant signal for either the MK or MWU test in my 40kb neighborhood of that element (Table A.2). Another noteworthy negative result on these tests is the harseq6 region, which has an extremely elevated rate of mutation as estimated either by nucleotide diversity [76] or by the number of segregating sites [80] (Table A.1), but apparently no strong bias towards weak-to-strong fixation (Table A.2).
Although the MK test, like the MWU test, is consistent with the mechanism of BGC favoring fixation of G or C alleles, in fact only one of my regions (harseq1) had significant results in both tests. Since the original identification of these elements as HARs depended on substitutions fixed on the human lineage, it is not surprising under the assumption of BGC to find that a bias towards W2S fixation is associated with the HAR neighborhoods. The complementary evidence from the MWU test (a total of 20 of my 49 test regions are W2S-significant on one test or the other) indicates that the ongoing bias in favor of W2S mutations has also probably led to human specific substitutions in otherwise conserved elements.
The Scale of Fixation Bias towards Weak-to-Strong Mutations Because BGC is posited to operate on a scale much smaller than the 40kb of my target sequencing regions, perhaps operating at localized recombination hotspots, and because the (100–400bp) HAR elements at the core of my target regions were suspected of arising in part due to BGC [59], I wanted to test whether the MWU and MK signals depended on these core elements. I therefore performed the same tests after masking out the central 500bp, 1kb, 5kb or 10kb of each region.
I found that signals of both ongoing and historical fixation bias are fairly robust to removing sequences including and flanking the core HAR element. For the MWU test, all but two (harseq1, harseq18) of the 11 regions that were significant at the 5% level for the MWU test were still significant at that level with the central 5kb omitted.
Seven of the 11 remained significant even with 10kb omitted (Table 3.1). For the MK test, the results were slightly more sensitive to masking. Considering the 11 regions with a significant result on that test (including the one favoring S2W fixation), 9(7) of these were still significant with the central 1kb(5kb) masked out (Table 3.2). I conclude that the evolutionary forces behind these results is not confined to the small HAR elements themselves, but rather that any bias in the substitutions found in the HARs is likely a byproduct of the forces acting at a larger scale.
To test whether there might be other localized elements within the 40kb regions driving these results I performed the tests under a set of fifteen overlapping 5kb masks (centered at a 2.5kb spacing along each region). Among the 11 MWU significant regions, 5 were still significant at 10% under this regime, while 3 completely lost significance (p > 20%) for at least one such mask (Table 3.1). Of the 11 MK significant regions, 5 were still significant at 10% (including harseq1) under this regime, while 1 completely lost significance (p > 20%) under at least one mask (Table 3.2). It is worth noting that the harseq1 result reflects the fact that of the 105 segregating sites I found in that 40kb neighborhood, 71 were S2W and only 19 W2S (Table A.2).
I conclude from this set of tests that the evolutionary forces behind W2S fixation bias are not necessarily highly local. If fixation bias relies on recombination hotspots and BGC, I have to posit that such hotspots extend over a long range of bases, or are somehow temporally and spatially variable.
No Significant Evidence for Selective Sweeps For each of the studied regions, I used the SFS to calculate two population genetic statistics that can sometimes indicate positive selection: Tajima's D [75], which is based on the folded SFS, and Fay and Wu's H [23]. Neither of these statistics exceeded the value of ±2 in any region (Table A.1). I next compared the distributions of these two statistics in the 49 harseq regions and the 13 ctlreg regions, to those for the same population (YRI) in 104 genic regions resequenced by Seattle SNPs (see Section 3.2.7). I found the ctlreg regions to be indistinguishable from the Seattle SNPs for these statistics, while the harseq regions were only mildly more negative for Tajima's D (Wilcoxon rank sum p-value = 0.08) and not significantly different for H (Figure 3.2). These results strongly suggest that the site frequency spectrum in harseq regions is indistinguishable from that found in either my control regions (ctlreg), or in the Seattle SNPs data set.
Thus there is no reason to believe that harseqs represent some kind of genomic outlier with respect to recent selective events.
To test for evidence of a selective sweep, I analyzed the spatial variation of de- rived allele frequencies at the segregating sites from my 22 chromosomal samples in each of the target 40kb regions using the SweepFinder program. This software determines a composite likelihood ratio (CLR) statistic comparing the hypothesis of a complete selec- tive sweep at the location to the null hypothesis of no sweep using Test 2 from Nielsen et al. [52]. I tested along a grid of 1000 points in each target region. This test has been shown to be robust to demographic deviations from the standard neutral model in its ability to use an arbitrary background site frequency spectrum [82]. I tested with two such backgrounds: the first from the pooled set of all the data in the 49 harseq regions plus 13 ctlreg regions, the second from the same population (YRI) as my samples but with frequencies taken from the Seattle SNPs resequencing data [4] for a large set (104) of genic regions. It should be noted that using the SFS from my data as the background harseq1to49 vs p2seasnpgenes Wilcoxon 2−sided p−value = 0.08156
ctlreg50to62 vs p2seasnpgenes Wilcoxon 2−sided p−value = 0.9931

harseq1to49 vs p2seasnpgenes Wilcoxon 2−sided p−value = 0.1303
ctlreg50to62 vs p2seasnpgenes Wilcoxon 2−sided p−value = 0.6303
Figure 3.2: Comparison of Population Genetic Statistics in harseq regions andSeattle SNPs genes. Boxplots show the distribution of Tajima's D, Fay and Wu's H in my test regions (harseq1-49), my control regions (ctlreg50-62) and YRI samples sequenced in 104 Seattle SNPs to define the neutral model should be particularly conservative in that I am testing any given region for deviations from that neutral model. To determine the significance of the maximum CLR values, we performed coalescent simulations of each target region and ran the SweepFinder program on each simulated set of segregating sites as described in Section 3.2.5. I report as a p-value the fraction of simulations of each target that had a CLR greater than or equal to the actual maximum CLR for that target (Table A.2) The harseq regions with the most significant five SweepFinder p-values are listed in Table 3.3. These are nearly all at the 95% confidence level for either of the two background distributions used, but I note that none are individually significant after a conservative Bonferroni correction, given the 49 harseq regions that were tested. Since these may nevertheless harbor mutations that were selected for in the human lineage, here I briefly note some of their characteristics that can be seen in tracks from the UC Santa Cruz Genome Browser (Figure 3.3).
Table 3.3: SweepFinder Hits Target regions with most significant p-values for SweepFinder.
Har,Sea refer to null model background frequency spectrum derived from all target regions or Seat- tleSNPs respectively. RecA and RecM are the sex-averaged or male only recombination rates at the target region. karyo is the chromosomal karyotype band where the target region is found.
Unlike the other four SweepFinder hits, which all contain introns or exons of coding genes, harseq25 is in a gene "desert". The nearest known gene, approximately 1Mb away on chromosome 4, is ODZ3, which is a transmembrane signaling protein most 23 q24 q25 4q26 27 A harseq25
SweepFinder CLR on harseq resequencing. bgrnd sfs = seasnp. gridsize = 1000 Segregating sites from harseq resequencing. Reddish for higher derived frequencies Placental Mammal Basewise Conservation by PhyloP Human Accelerated Regions B harseq9
SweepFinder CLR on harseq resequencing. bgrnd sfs = seasnp. gridsize = 1000 Segregating sites from harseq resequencing. Reddish for higher derived frequencies UCSC Genes Based on RefSeq, UniProt, GenBank, CCDS and Comparative Genomics Placental Mammal Basewise Conservation by PhyloP Human Accelerated Regions C harseq11
SweepFinder CLR on harseq resequencing. bgrnd sfs = seasnp. gridsize = 1000 Segregating sites from harseq resequencing. Reddish for higher derived frequencies UCSC Genes Based on RefSeq, UniProt, GenBank, CCDS and Comparative Genomics Placental Mammal Basewise Conservation by PhyloP Human Accelerated Regions D harseq16
SweepFinder CLR on harseq resequencing. bgrnd sfs = seasnp. gridsize = 1000 Segregating sites from harseq resequencing. Reddish for higher derived frequencies UCSC Genes Based on RefSeq, UniProt, GenBank, CCDS and Comparative Genomics Placental Mammal Basewise Conservation by PhyloP Human Accelerated Regions E harseq24
SweepFinder CLR on harseq resequencing. bgrnd sfs = seasnp. gridsize = 1000 Segregating sites from harseq resequencing. Reddish for higher derived frequencies UCSC Genes Based on RefSeq, UniProt, GenBank, CCDS and Comparative Genomics Placental Mammal Basewise Conservation by PhyloP Human Accelerated Regions Figure 3.3: SweepFinder Composite Likelihood Ratio (CLR) in genomic con-text. For the indicated harseq regions, the SweepFinder results are shown along with the segregating sites from my sequencing – more reddish for those with higher derived allele frequencies. Other tracks show introns and exons of known genes and evolutionary conservation. The CLR peaks are not strongly associated with the core HAR elements.
highly expressed in brain. Note that harseq25 also has a significant result on the MWU test discussed above.
Evidence for a sweep in the harseq9 region is intriguing because it encompasses the 42-codon long, second exon of the PTPRT gene, a phosphatase with possible roles in the central nervous system. However, the human amino acid sequence of this exon matches the other primates chimp, gorilla, and orangutan, except where chimp has an obviously non-ancestral Thr>Ala substitution. The human sequence does have a single G>A substitution near the 3' splice site just upstream of this exon, but it falls in a position between the polypyrimidine (Py) tract and the AG acceptor site, for which the consensus sequence across many splice sites is evenly divided among the 4 nucleotides.
The location of harseq11 on chromosome X places its evidence for a sweep in the first intron of the 2.4Mb long dystrophin gene DMD. The evidence for a sweep in harseq16 is offset to one end of its region, about 20kb from an apparent pseudogene comprising a single coding exon with a 270-codon open reading frame (ORF) that is probably derived from the Poly-A binding protein PABPC1.
The harseq24 region encompasses the second through fourth exons of the SKAP2 gene with the strongest evidence for a sweep about 10kb from the closest exon, but closer to a LINE transposable element that is present also in chimp, orangutan, and rhesus macaque (but lost in gorilla).
Although I found only weak evidence for selective sweeps, and none that seems to point directly to a mutation in a core HAR element based on the position of the SweepFinder peak CLR values, it is important to note that while having the advantage of robustness to demography and recombination rate, my tests would not likely have power to detect sweeps that occurred beyond the last ∼200,000 years [82].
Methods for HAR Neighborhood Analysis Sample Data Genomic DNA Selection Genomic DNA for my samples was obtained from the NHGRI Sample Repos- itory for Human Genetic Research distributed by the Coriell Institute for Medical Re- search [Camden NJ] [1]. All of the 11 samples were chosen from the Yoruba from Ibidan Nigeria (YRI) HapMap population. In particular, the samples were chosen as a subset of the Seattle SNPs P2 panel [4]. The Seattle SNPs PGA-VDR (and Coriell repository numbers were): DY01(NA18502), DY03(NA19223), DY04(NA19201), DY17(NA19143), DY18(NA18517), DY19(NA18856), DY20(NA19239), DY21(NA18871), DY22(NA19209), DY23(NA19152), DY24(NA19210). Sample preparation as described below was similar for all samples, except that prior to processing, the DY01,DY03,DY04 samples were subject to whole genome amplification (WGA) using the Repli-G Kit (Qiagen N.V, The Netherlands) according to manufacturer's specifications. It was found that WGA caused a loss of coverage in some isolated target regions, most notably in the 28kb section of the harseq1 region with coordinates hg18:chr20:61,183,966–61,212,244, except for the core HAR1 element at chr20:61,203,919-61,204,081.
Target Regions and Nimblegen Enrichment Array Design The primary target regions consisted of 20kb extensions in both directions from the 49 most statistically significant Human Accelerated Regions (HARs) identi- fied as having a 5% false discovery rate [60]. Additional 40kb control regions were chosen in neighborhoods of 13 of the set of 34,498 vertebrate conserved elements that had extremely low likelihood ratio test (LRT) scores used to define the HARs. The enrichment arrays were obtained from Nimblegen Systems (Madison WI) who designed the probes on their 385K array based on my specifications of the coordinates of the 62 target genomic regions (Table A.1). Probes were chosen to tile the target regions from both DNA strands. The design process avoided probes in highly repetitive sequences as described previously [53, 5]. The fraction of bases in the target regions covered by the probes ranged from 98% (harseq12) to 65% (harseq4) with a median of 88%. Details of probed bases are available upon request.
At the time that I designed the enrichment array the main alternative tech- nology for genomic DNA enrichment was to use oligonucleotide probes in solution. A solution based method presumably would have better kinetic properties than the array based method. However, the main drawback is cost. Synthesizing individual oligonu- cleotides at a cost even as low as $0.10 per base would be prohibitively expensive to cover target regions encompassing 2M bases. A commercially available alternative from Agilent Technologies was also available based on their array technology in which they separated the probes from the array after fabrication. This approach was successfully used for enrichment of sets of exons in the human genome [61] but the cost was still relatively high, since this technology provided 55,000 probes for about $10,000. Com- pared to the 385,000 probes on the Nimblegen array (at about $1,000 per array) this would have been much more expensive to cover my target regions, even considering the fact that one order of Agilent probes would have sufficed to enrich DNA from all of my SOLiD Barcoded Library Preparation The library preparation of the samples for SOLiD (Applied Biosystems, Fos- ter City, CA) sequencing generally followed the manufacturer's protocols for barcoded SOLiD System 2.0 Fragment Library Preparation (samples DY01,DY03,DY04) and SOLiD System 3.0 Barcoded Fragment Library Preparation (remaining samples), with changes as necessary for enrichment on the Nimblegen arrays as noted in the following: Samples were sheared to approximately 100bp using the Covaris S2 System Program B (Covaris Inc, Woburn, MA). End repair was performed with End-It DNA End-Repair Kit (Epicentre Biotechnologies, Madison, WI) per manufacturer's instructions. Single stranded oligos for the P1 and P2-barcoded SOLiD adaptors were ordered from In- vitrogen Corporation and annealed per the SOLiD protocol to form double stranded adaptors, which were ligated to the end-repaired DNA fragments using the Quick Lig- ation Kit (New England BioLabs, Ipswich, MA) per manufacturer's directions, leaving a nick at the 3' end of each genomic DNA strand where the 5' end of the adaptor was not phosphorylated. Samples DY01,DY03,DY04 were size selected to 150∼250bp from a 6% polyacrylamide gel and purified via ethanol precipitation. This was followed by nick translation and ligation mediated PCR (LMPCR) amplification (6 cycles) in a combined reaction per the SOLiD protocols using Takara ExTaq polymerase (Takara Bio, Madison, WI). After dividing into 10 aliquots, an additional 10 cycles of ExTaq LMPCR amplification were performed on these samples in preparation for array hy- bridization. Samples DY17-DY20 were first nick translated without amplification using Pfu polymerase (Stratagene, La Jolla, CA). Samples DY21-DY24 were nick translated and ExTaq LMPCR amplified (6 cycles). Quantitation using a DNA 2100 BioAnalyzer (Agilent Technologies, Waldbronn, Germany) showed that the PCR associated with nick translation prior to size selection mainly served to amplify the nick translated adaptors.
After the nick translation and any initial LMPCR, all of samples DY17-DY24 were size selected on an E-Gel SizeSelect 2% agarose gel (Invitrogen) per manufacturer's instruc- tions. These size selected samples were then ExTaq LMPCR amplified (6, 9 or 10 cycles) in preparation for array hybridization.
Array hybridization to the Nimblegen arrays was performed on the Nimble- gen Hybridization System 4 station under Mix Mode "B" for 64 to 70 hours using the Nimblegen Sequence Capture Kit per manufacturer's instructions. Prior to hybridiza- tion, samples DY21-24 were pooled to a total of 5.7µg. All the other samples were hybridized individually, in amounts ranging from 1.9µg to 8.0µg per sample. For com- petitive hybridization to probes on the array that might nonselectively bind repetitive DNA, Human Cot-1 DNA (Invitrogen) that had been Covaris sheared to approximately 100bp was added to the hybridization mix in a 5:1 ratio by weight. Additionally, to block the adaptor ends of the denatured, single stranded DNA fragments from binding to each other, a 10:1 molar excess of adaptor oligos (P2 with an unused barcode sequence and P1) was also added. At the completion of hybridization, the slide was washed with the Nimblegen Sequence Capture Wash and Elution kit per manufacturer's directions, and the enriched DNA was eluted with 350µL of 75◦C purified water using an affixed SA200 SecureSeal Hybridization Chamber (Grace Bio-Labs, Bend OR). A secondary elution with an additional 350µL was also taken. Quantitative real-time PCR (qPCR) was performed on the eluted material to determine the rough fraction of target DNA and to compare the primary and secondary elutions. For this purpose qPCR amplicons within the target were compared to amplicons not in the target regions. It was gener- ally found that the primary elution captured more than 95% of the target DNA (data not shown). By normalizing to pre-enrichment material, and taking into account the fact that the 2.1Mbp target region comprised approximately 0.1% of the entire human genome, it was estimated that more than 35% of the eluted material fell in the target regions (data not shown).
The eluted material was ExTaq LMPCR amplified (samples DY01 for 19 cy- cles, samples DY03-04 for 15 cycles, pooled samples DY21-24 for 10 cycles, samples DY17-20 for 12 cycles,) in preparation for the emulsion PCR step of SOLiD sequenc- ing that was performed in the UC Santa Cruz Genome Sequencing Center. Samples DY01,DY03,DY04 were processed with the SOLiD Version 2 system, producing 35 bases of sequence information for each read. The remaining samples were processed with the SOLiD Version 3 system, producing 50 bases of sequencing information for each read.
Sequence Mapping, Filtering, and Genotyping The 35mer (DY01,DY03,DY04) or 50mer (remaining samples) sequencing reads were mapped to the whole human genome using the bwa program [43] which generates mappings and associated quality scores in the sam format [44] that can be processed with the samtools suite. The bwa program is aware of the colorspace nature of the SOLiD sequencing reads, and uses a dynamic programming algorithm to infer the best nucleotide sequence for the read [43]. All reads were also mapped to the DNA of the Epstein-Barr Virus, which was used to transform the Coriell cell lines from which the supplied genomic DNA was extracted. For the female samples, the Y chromosome was excluded from the mapping. For the male samples, the pseudo-autosomal region of the Y chromosome was excluded from the mapping. The set of mappings for each sample was then filtered to the regions covered by the probes on the Nimblegen enrichment array described above. To eliminate spurious pileups caused by overamplification of particular molecules in the library preparation process, the mapped reads were further filtered to select at most 4 reads from each strand at a given genomic starting posi- tion. Where there were more than 4, the 4 with the highest total read quality (not the best mapping quality, which would bias against reads containing non-reference al- leles) from the SOLiD instrument were selected. Between 40% and 60% of the reads for a given sample were successfully mapped, and of those reads, between 33% and 48% mapped to bases covered by the probes on the enrichment array (Table 3.4). For samples DY01,DY03,DY04 about 50% of the latter reads were lost in the "maximum 4 per strand" pileup elimination step, while only 11% to 23% were lost in this step in the remaining samples (Table 3.4 and Figure 3.4). This was likely due to the difference in LMPCR cycles used for the different samples as noted above.
To determine the coverage at each position in the target region and the con- sensus genotypes for each sample, the command "samtools pileup -v" was used with default parameters for its consensus calling model. Possible confounding of the geno- types due to contamination by paralogous sequences was avoided in two ways. First, as noted, only genotypes at positions delimited by the Nimblegen probes were used in the analysis and these probes were designed to avoid repetitive sequences. Second, the bwa mapping algorithm assigns low mapping quality to reads that are not genome-wide unique, and the samtools consensus caller requires high mapping quality. To filter SNPs from among the not homozygous reference genotypes, "samtools.pl varFilter" was run with default parameters, except that the maximum read depth was set to 425, because with up to 4 reads of length 50 on each strand, it was possible to get coverage of 400.
This command filters out potential SNPs when more than 2 fall within a 10bp window, on the grounds that there might be an insertion/deletion event rather than separate SNPs, and also filters out reads with RMS mapping quality value less than 25. A sim- ilar quality filter was applied to the genotype calls that were homozygous reference.
Because of stochastic variation in the composition of reads from the two chromosomes of each diploid individual, low coverage might cause an erroneous homozygous call in a true heterozygote. Therefore a further filter restricted the subsequent analysis to the SNP or homozygous reference calls made for a sample only at positions for which the coverage was 35 or greater. For each target region, the count of the union of such posi- tions across all samples is listed in Table A.1. As shown in Figure 3.5, the vast majority of the segregating sites that remain after the application of my 35X coverage filter are in Hardy-Weinberg Equilibrium, with only 0.3% having a p-value less than 0.05.
Table 3.4: HAR Region Mapping Statistics M: million reads. Total: the total number of reads obtained for a given sample. Mapped: the subset of Total that mapped successfully to the human genome. mapFrac is Mapped/Total. Probed: the subset of Mapped that mapped to the regions defined by the probes on the Nimblegen enrichment array. probeFrac is Probed/Mapped. 4Best: the subset of Probed that remain after filtering to allow at most 4 reads from each strand at each starting position in the genome. 4bestFrac is 4Best/Probed. Sample DY02 was not included in the analysis because 97% of its on-target reads were removed in the "4best" pileup elimination step.
Derived Allele Frequencies and SweepFinder For purposes of all subsequent analysis, an ancestral allele at each position in the target regions was determined from the Enredo-Pecan-Ortheus (EPO) pipeline [54, 55] as published on the 1000 Genomes website [2]. This pipeline determines the common ancestor of human and chimp at a locus by considering alignments of the human, chimp, orangutan, and rhesus macaque genomes.
Figure 3.4: HAR Region Mapping Statistics by Sample. Graphical representation of the data in Table 3.4. Although the starting number of reads ("Total") varied widely across the samples, roughly the same number of reads ("4Best") were used for genotyping each sample. As noted in Table 3.4 sample DY02 was excluded from the analysis.
Histogram of HWE p−values (two.sided)
N−total= 5835 N−pval<0.01= 1 N−pval<0.05= 17 N−pval<0.10= 56
umber of segsitesn Figure 3.5: Histogram of Hardy-Weinberg Equilibrium Test. Histogram of the p- values obtained in a 2-sided test for Hardy-Weinberg equilibrium across all of the SNPs used in the analysis of my test (harseq) and control (ctlreg) regions. The vast majority conform to the HWE From the sets of filtered genotype calls in the 11 diploid samples as described above all the segregating sites were selected. A set of filters was applied to this list to produce the final set of segregating site derived (i.e. non-ancestral) allele frequencies (DAFs) for all downstream analyses. To avoid skewing the DAFs towards higher fre- quencies, segregating sites with less than 8 chromosomal samples were eliminated. Also eliminated were any positions with more than 2 alleles among the reference, ancestral, or sample alleles, or where the ancestral allele was not determined by the EPO pipeline.
Lowercase values of the EPO ancestral allele, which result from various cases without complete evidence in all species were not eliminated.
The SweepFinder program [52] was applied to the allele frequencies for the final list of segregating sites to determine the composite likelihood ratio (CLR) of a selective sweep at each one of a grid of 1000 positions across each target region. The model used in this program requires a background derived allele frequency spectrum.
Two such backgrounds were used. First, all of the DAFs from all filtered segregating sites in my sample were aggregated and used as input to the command "SweepFinder - f", which accounts for missing data using a Broyden-Fletcher-Goldfarb-Shanno (BFGS) algorithm. I refer to this as the "harseq" background. A second, presumably more neutral background was obtained from the African-Derived (AD) YRI subset of 24 individuals in the Seattle SNPs P2 panel. The DAFs for all segregating sites in all 104 genes resequenced for this panel by Seattle SNPs [4] were included. As for the harseq background, the "seasnp" background was obtained with the command "SweepFinder -f" applied to these DAFs. The resulting "seasnp" frequency spectrum ran from 1 to 47 and was reduced to a spectrum running from 1 to 21, as needed by SweepFinder with my data, by hypergeometric weighting the relevant components of the input Xj(j = 1.47) allele frequencies at each target Yi(i = 1.21) allele frequency.
Dividing by the sum of the Yi in Eqn 3.1 produces a valid frequency spectrum that sums to 1. A similar hypergeometric weighting was also required to reduce the spectrum to a range from 1 to 19 for the harseq1,2 and ctlreg60 regions. In the latter regions missing data reduced the maximum number of samples at the segregating sites to 20. The reasoning behind the hypergeometric weighting can be understood from an example. Consider a site for which, among 48 samples, there are 6 derived and 42 ancestral alleles.
At this site a subsample of 22 from the 48 samples has some probability P3,6 of having 3 derived and 19 ancestral alleles that can be calculated as follows. Think of the site as an urn with 6 "D" balls and 42 "A" balls. There are 48 possible subsamples. For each of these subsamples there are 6 ways to choose 3 "D" balls and 42 ways to choose 19 "A" balls from the urn. So the probability P hypergeometric factor 6 42/ 48. Now if there are M 6 such sites, the expected number of such sites for which the subsample has 3 derived alleles is given by N3,6 = M6P3,6.
For other sites with at least 3 (of 48) derived alleles and at least 19 (of 48) ancestral alleles similar calculations can be made and then summed to get the total expected number of sites with 3 (of 22) derived alleles N3 = P MjP3,j. Dividing both sides by the total number of sites yields equations in the form of Equation 3.1. The additional normalization step is required because it is possible for many of the subsampled sites to yield either 0 or 22 derived alleles, but we are only interested in sites which are segregating in the subsample.
MWU and MK tests on Harseq and Ctlreg Regions To determine if mutations from an ancestral weak (A or T) basepair to a strong (G or C) basepair (W2S mutations) are more likely to spread in the popula- tion represented by my samples, I compared W2S segregating sites to S2W segregating sites for each target region and for the aggregate set of segregating sites. I performed a Mann-Whitney U (MWU) test for a difference between the W2S and S2W derived allele frequency spectra. The test was performed in the R language with the command "wilcox.test (paired=FALSE, alternative=two.sided)". The resulting "location" param- eter was normalized to 22 samples and is positive if W2S mutations are segregating at higher frequencies than S2W. The resulting p-values are in Table A.2.
To determine if relatively more W2S mutations fixed along the human or chimp lineages than are segregating in the human population represented by my samples, I first determined the high mapping quality chimp reference bases that differ from the human reference using reciprocal best alignments of the chimp and human genomes [38]. This set was then restricted to the positions in my target regions for which I had a genotype call for at least one sample with read depth of coverage of 35 or greater as discussed above. From this set of fixed differences I removed any for which the EPO ancestral allele was not determined as discussed above, or for which I had a segregating site, or which appeared in dbSNP release 129 [71]. The remaining fixed differences as well as the segregating sites were divided into W2S or S2W (or other). A McDonald Kreitman-like (MK) test on the resulting 2x2 contingency table was performed in the R language with the command "fisher.test (alternative=two.sided)". The resulting p- values are in Table A.2. For the significant cases it was easy to determine from the data in the contingency table if the fixed differences favored S2W mutations relatively more than the segregating sites (column "S2W" in Table 3.2).
For the target regions with significant p-values on either the MWU or MK tests, I tested whether the significance was due to a restricted locus within the region, by removing all segregating sites and fixed differences under a mask of a given size at a given position within the region and rerunning the test with the remaining data (Table 3.1 and Table 3.2).
MWU and MK Tests on Seattle SNPs Regions and Simulations I downloaded the data for the 104 genes resequenced with the Seattle SNPs P2 panel. The genotypes for my 11 YRI samples (which are a subset of the P2 panel) and the coordinates for the genotyped segregating sites were obtained from the global "pret- tybase" file mapped to UCSC hg18 coordinates. The total set of positions genotyped was obtained from the individual gene "genbank" files by excluding the features defined as "Region not scanned for variation" and aligning the remaining regions to the hg18 coordinates of the full extent of the genic region sequenced specified in the associated "ucscDataFile". Given these coordinates and the genotypes at the segregating sites, the same techniques as described above for my resequencing data was applied to derive ancestral alleles and human/chimp fixed differences, and to perform the MWU and MK My data was derived from (probed) regions of a relatively tight size distribu- tion (Table A.1). By contrast, the sizes of Seattle SNPs variation-mapped genic regions varied widely. Some were rather small and contained few segregating sites. Therefore, I included only genic regions with a minimum of 10kb variation-mapped and a minimum of 40 segregating sites. Additionally, a small number of the genic regions were excluded because of data missing from the "prettybase" file or because there were no associated high quality reciprocal best human-chimp differences as described above, possibly be- cause of paralogous genes in one or the other lineage. The remaining set of results for the MWU and MK tests on 62 genic regions (Table A.3) were used for comparison to my 49 harseq regions.
To determine if the p-values for the MWU and MK tests were accurate, I also conducted the tests on sets of simulated data. For the MWU test, I performed coalescent simulations using Hudson's ms program [32]. For each simulation I generated 22 samples at 85 segregating sites (the average number of W2S plus S2W segregating sites in the 49 harseq target regions) and then randomly assigned the sites as either W2S or S2W in Bernoulli trials using the W2S:S2W ratio from the 49 harseq regions of 2057:2114. After calculating the MWU test p-value for each simulation, the fraction of simulations with p-value less than a given value was computed, as well as the subset of that fraction in which the W2S spectrum was offset towards higher derived allele frequencies (Figure 3.6).
Fraction of Simulations by MWU−test p−value
all (slope = 0.998) W2S (slope = 0.513) Figure 3.6: Accuracy of MWU Test p-values. For a given p-value the fraction of neutral model simulations having that p-value or better on the MWU test is shown. Red circles: all simulations with a better p-value. Blue squares: the simulations with a better p-value for which the weak-to-strong (W2S) spectrum is offset towards higher frequency. Regression lines are shown with the slope indicated in the legend. For a given p-value the W2S-biased simulations comprise about half of all simulations.
For the MK test, for each simulation I separately derived a set of human- chimp fixed differences and a set of segregating sites. The fixed differences were derived using the phyloBoot program from the PHAST package [72]. I used a phylogenetic model and substitution rate matrix derived from 4-fold degenerate amino-acid coding synonymous sites across the genome as an unbiased neutral model. The equilibrium GC-content of this model was adjusted to reflect the genome-wide average GC-content.
From the primate sequences so generated, I extracted positions containing a human- chimp difference that could also be unambiguously assigned an ancestral allele based on the macaque allele at that position. Each simulation used 335 such sites, (the average number of fixed differences in the 49 harseq target regions) which were divided based on whether they were W2S or S2W (or other). The segregating sites for each simulation were derived from 101 (the average total number of segregating sites in the 49 harseq target regions) Bernoulli trials, randomly dividing them as W2S or S2W (or other) according the corresponding ratios in the fixed differences from all of the phyloBoot simulations. After calculating the MK test p-value for each simulation, the fraction of simulations with p-value less than a given value was computed, as well as the subset of that fraction for which the ratio of W2S:S2W was higher for the simulated fixed differences than for the simulated segregating sites (Figure 3.7).
Fraction of Simulations by MK−test p−value
all (slope = 0.865) W2S (slope = 0.426) Figure 3.7: Accuracy of MK Test p-values. For a given p-value the fraction of neutral model simulations having that p-value or better on the MK test is shown. Red circles: all simulations with a better p-value. Blue squares: the simulations with a better p-value for which the weak-to-strong (W2S) fraction is relatively higher in fixed differences than segregating sites. Regression lines are shown with the slope indicated in the legend. The p-values are conservative in that they overestimate the fraction of simulations at a given significance level. For a given p-value the W2S-biased simulations comprise about half of all simulations.
In the era of comparative genomics, strong signals of conservation across mul- tiple species serve as signposts that can indicate regions where evolutionary forces may be preserving functional elements that are subject to purifying selection. By contrast, signals of positive selection pointing to adaptive changes in one lineage are harder to find, often employing sets of polymorphic sequences from multiple individuals of the same species.
In this work I have addressed both of these aspects of the evolutionary history of the human genome. In my work on the Ultraconserved Elements (UCEs) I employed resequencing data for a large number of samples that was obtained using classical meth- ods based on PCR followed by capillary electrophoresis Sanger sequencing. From this resequencing data I identified polymorphic positions and then derived and analyzed the derived allele frequency (DAF) spectrum of these polymorphisms. The results of my analysis clearly show that these elements, taken as a whole, are under strong selective constraint. This constraint is in fact much stronger than that at play in protein coding sequences. This result effectively laid to rest any speculation that these elements are merely mutational cold spots, lacking any likely function. An important challenge that was overcome in this work was the inherent ascertainment bias in the definition of these elements wherein polymorphic positions at high derived allele frequency are likely to prevent a region from being defined as ultraconserved. An especially striking aspect of my results was that the bases immediately flanking the UCEs are apparently subject to much weaker selective forces.
Although these conclusions about the UCEs are important, they are only ap- plicable to the UCEs as an aggregate because the analysis of the DAF spectrum was only possible using all the polymorphisms found across these elements. Most individual UCEs have zero, one or two SNPs. Thus it was not possible to make statements about the strength of selection of particular elements, nor to infer if any are in fact more likely to be functional than others.
By contrast, my analyses of the HARs were applied separately to a 40kb neigh- borhood of each region. I exploited the two recently developed techniques of genomic enrichment and high throughput sequencing to characterize the polymorphism in a sin- gle human population across these neighborhoods of the 49 HARs (harseq regions). I investigated the harseq regions because the HARs were defined based on a presump- tion that the human lineage specific fixed differences therein might have arisen due to adaptive evolutionary forces. On the other hand, it has been emphasized by some that the presumably evolutionarily neutral mechanism of biased gene conversion (BGC) can influence the frequency spectra at polymorphic positions, or cause fixation of alleles in a way that partially mimics the action of adaptive evolution. Indeed, fixation bias was noted in connection with the limited set of human specific alleles for some of the HARs when they were first described [59].
With the extensive novel polymorphism in my samples, I was able to carefully characterize fixation bias — both historical and ongoing — in the harseq regions and to conduct tests for recent selective sweeps across these regions. Like my resequencing data for the UCEs, my harseq resequencing data eliminates issues of SNP ascertainment bias that could have skewed previous investigations of polymorphism near HARs.
Consistent with published reports [59, 17, 26], I found evidence of historical W2S fixation bias in harseq regions. Using a MK test, I compared the proportion of W2S mutations among already fixed substitutions on the human or chimp lineage to that among the still segregating sites in my samples. I found that 11 of the 49 regions show statistically significant evidence of historical bias in allele fixation, with all but one favoring W2S fixation. These results strengthen and expand previous findings by identifying signals for W2S bias in much larger regions flanking the core HAR regions in an ascertainment-free population sample.
But my work goes beyond previous approaches by also looking at ongoing W2S fixation bias in the segregating site frequency spectrum. I performed a MWU test using only sites that are still segregating in the human population, separating out W2S from S2W mutations. This second test is designed to detect a phenomenon of bias that is currently driving W2S mutations to higher frequency in the population than S2W mutations. I found statistically significant evidence for this bias (and none in the opposite direction) in the regions flanking 11 of 49 HARs.
For both tests, I showed that the core HAR element is generally not the main source of the signal that was detected, since the signal usually remains strong even when I mask out the central 1kb or even 5kb of the region. This is not consistent with BGC due to a recombination hot spot that has remained in the same location for millions of years, because the length scale of the effect of BGC is set by the length of the heteroduplex tract formed during recombination that needs to be repaired, which is thought to be ∼500bp (e.g. [11, 65, 25]). However, it is consistent with a model in which the location of recombination hotspots drift fairly rapidly over evolutionary time scales, but may be denser in some regions [64, 58, 48, 15, 57].
It is noteworthy that there was little overlap in the regions identified by these two tests, one for older W2S fixations and the other for present day forces toward fixation, with a total of 20 found in one or the other.
This is consistent with the hypothesis that the regional focus of BGC, which may be recombination hot spots, drifts significantly on a time scale of many hundreds of thousands or millions of years.
Another explanation for W2S fixation bias near HARs is selection for increased GC-content or individual fitness-improving GC alleles. To investigate these hypotheses and to attempt to disentangle the possible roles of BGC and positive selection in shaping the HARs, I applied a recently developed powerful method for detecting selective sweeps.
Selection was previously investigated in much larger (∼500kb) regions using more sparse polymorphic loci [82]. That study found 101 regions with strong evidence for a selective sweep within 100kb of a known gene. Here, I found only weak evidence for selection comprising 5 possible candidates for such sweeps among 49 target regions. As we are dealing with a lineage-specific evolutionary period of about 5 million years, and these tests can only see back a few hundred thousand years, it is quite possible that the original signal for selective sweeps in these regions has already decayed beyond our ability to recognize it in human population genetic data.
Consistent with the idea that HAR regions may have experienced positive se- lection too long ago to be detected with population genetic methods, very few positively selected regions in the human lineage have been identified to date, despite the existence of numerous public databases. Selective sweeps that have been identified have typically been the product of very recent events in human history, such as dairy farming affect- ing the lactase gene [8] or climate differences influencing a salt sensitivity variant [78].
Such environmental or cultural changes result in differences in the genetic makeup of disparate human populations, and such differences can be exploited to find evidence of recent, possibly still ongoing, selective sweeps.
Despite the evidence that the unusually high level of recent substitution in the more extreme HAR elements such as HAR1 is at least partly due to the non-selective process of BGC, there is ample evidence that some of these genomic elements remain functional, and thus that the effect of BGC was to mutationally stress but not destroy these elements. HAR1 shows a very strong pattern of compensatory substitutions within its RNA helix structures, indicating a selective force to maintain these helix structures.
The W2S substitutions all strengthen the RNA helices of HAR1, and in one case, a substitution appears to extend one of them. Thus, although the nominally non-selective GC-biased evolutionary force that I have documented may reduce the fitness advantage of some HARs, it is also possible that it has enabled some of these regions to attain a configuration subject to positive selection for higher fitness in humans.
In summary, I have investigated two sets of highly conserved genomic regions.
For both sets I have used polymorphism data from the present day human population to elucidate evolutionary forces at work. I have shown that purifying selection is likely preventing the UCEs from diverging in our species from the ancestral state, and that some of the base substitutions now evident in the HARs are likely to be the result of a process that favors fixation of mutations from weak to strong basepairs. As larger data sets of human genetic variation become available it should be possible to expand these results to the genome-wide scale.
Supplementary Tables HAR Region Statistics. Characteristics of the target (harseq1- 49) and control (ctlreg50-62) regions in the HAR study. hg18pos: chromosome coordinates in the hg18 human assembly. bpExp: the number of basepairs used in the experimental analysis. This number starts with the count of bases in the region that were included in probes in the Nimblegen array, but only includes bases for which sequencing coverage of at least 35X was reached for at least one sample, after removing pileups of more than 4 reads at the same starting point. AncGC: the GC percentage of the ancestral bases in bpExp.
θπ: estimate of the neutral mutation parameter (= 4Neu x104) via nucleotide diversity. θW : estimate of the neutral mutation parameter via the number of segregating sites. tajD: measure of skew in the folded site frequency spectrum.
faywuH: measure of skew in the unfolded site frequency spectrum.
HAR Region Test Results segsites (N): total number of segregating sites from my samples. fixed diffs (N): number of positions for which I had sufficient coverage to make a genotype call in at least one sample that have a fixed difference between the human and chimp reference, exclud- ing segregating sites and sites in dbSNP129.
w2s,s2w: subsets with weak- to-strong or strong-to-weak mutations from the ancestral basepair. MWUp- value,MWUoffset: p-value and estimated location offset (the latter normalized to 22 samples and estimated under the assumption that w2s and s2w have identical distributions) from Mann-Whitney U test comparing the frequency spectra of segsites w2s vs s2w, with positive values indicating W2S mutations shifted to higher derived allele frequencies. MKpval: p-value from McDonald- Kreitman-like test comparing the counts in w2s,s2w categories of segregating and fixed sites. SF: p-values for maximum CLR from SweepFinder run on the region with a background SFS derived from segregating sites pooled from all regions (Hpvalue) or from the same population segregating in Seattle SNPs resequenced regions (Spvalue).
Seattle SNPs Gene Region MWU and MK Test Results basepairs(Gene): total length of genic region. basepairs(Map): sum of base- pairs in regions that were mapped for variation within genic region. AncGC: the GC percentage of the ancestral bases in Map basepairs. segsites (N): to- tal number of segregating sites in Map basepairs for my samples. fixed diffs (N): number of positions in Map basepairs that have a fixed difference between the human and chimp reference, excluding segregating sites and sites in db- SNP129. w2s,s2w: subsets with weak-to-strong or strong-to-weak mutations from the ancestral basepair. Other annotations as in Table A.2.
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